Modeling and Analysis of Tunisia's Productive System...32 2.3.2 Global Demand Trend for Tunisian...
Transcript of Modeling and Analysis of Tunisia's Productive System...32 2.3.2 Global Demand Trend for Tunisian...
AfricanDevelopment Bank
(AfDB)
Tunisian Institute of Competitiveness andQuantitative Studies
(ITCEQ)
Economic Developmentand International
Finance Research Centre (DEFI)
Mr. Vincent Castel, Principal Program Coordinator, ORNA.
Mrs Natsuko Obayashi,Principal Country Economist,ORNA.
Mr. Hatem Haj Salem, Senior Operation Assistant,ORNA.
Mrs Kaouther AbderrahimBen Salah, Economist, ORNA.
Mr. Abdel Majid Ben Khlifa,Chief Economist, ModellingDepartment.
Mr. Ammar Saleheddine, IT Expert, Department of Information and KnowledgeSystem.
Mrs Mounira Bouali, Principal Economist, Department of Economic Studies.
Mrs Raoudha Hadhri, Principal Economist, Competitiveness Department.
Mrs Ikram Nahdi, Principal Economist, Modelling Department.
Mrs Samiha Chaabani, Principal Economist, Competitiveness Department.
Mrs Manel Gaaloul, Principal Economist, Department of Economic Studies.
Mr. Gilles Nancy, Professor, Aix-Marseille University.
Mr. Marcel Aloy, Maître de Conférences, Aix-Marseille University.
Mr. Eric Heyer, Professor, Sciences Po Paris.
Mr. Gilbert Cette, Associate Professor, Aix-Marseille University.
Mrs Marion Dovis, Maître de Conférences, Aix-Marseille University.
Mrs Patricia Augier, Maître de Conférences, Aix-Marseille University.
Mr. Pedro AlbuquerqueAssociate Professor, Minesota University.
Mr. Mikael Gaziorek, Professor, Sussex University.
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Acknowledgements
This report was prepared based on a study on the Tunisian
productive system. It was funded by a grant from the Fund for
Middle Income Countries of the African Development Bank (AfDB).
This study is part of a capacity building of the Tunisian Institute for
Competitiveness and Quantitative Studies (ITCEQ) and is the result
of a close collaboration between ITCEQ's research team and experts
from the Centre for Research in Development and International
Finance (DEFI) of the University of Mediterranean Aix-Marseille II.
The scope of the study has covered four selected themes which
are: (i) econometric evaluation of the production factors (added value)
and prices by manufacturing sectors, from the perspective of the
production system, (ii) the econometric evaluation of the demand
stream for Tunisian export products and services by sector in
the European market, taking into account both the European
manufactures and global suppliers. Due to the lack of sufficient data,
these sectorial econometric assessments have been completed by
a panel analysis (group of sectors), (iii) Analysis of the positioning of
Tunisian exports by product on worldwide markets from the
demand/supply perspective, as well as its evolution based on
standard key performance indicators. The objective of this analysis
is to identify new product/market mixes and increase export
opportunities, (iv) Analysis of the Tunisian productive system from
the perspective of business dynamics, to determine the composition
of the productivity gains in for the labor factor (aggregate level) in
several sources: internal business and / or across several phenomena
reallocation of resources. While the themes covered by this report
are different from different angles (methodological, nature, type of
database used and their objectives), they provide complementary
perspective on the Tunisian productive system. The ultimate objective
is to identify and implement the necessary reforms to improve
economic efficiency, further diversify the Tunisian economy while
seizing the opportunities offered by globalization and technological
development and gain access to new levels of stable and inclusive
growth.
The report also includes the description of the training activities
carried out under the capacity building program for the ITCEQ
team.
Thanks are also due to ITCEQ & DEFI researchers who contributed
to the following chapters:
Chapter I:
- DEFI: Mr. Gilles Nancy, Mr. Marcel Aloy and Mr. Eric Heyer
- ITCEQ: Mr. Abdelmajid be Khalifa and Mrs. Ikram Nahdi
Chapter II:
- DEFI: Mr. Gilles Nancy, Mr. Marcel Aloy, Mr. Eric Heyer and
Mr. Pedro Albuquerque
- ITCEQ: Mrs Raoudha Hadhri and Mrs. Samiha Chaabani
Chapter III:
- DEFI: Mr. Mikael Gaziorek
- ITCEQ: Mrs. Raoudha Hadhri and Mrs. Samiha Chaabani
Chapter IV:
- DEFI: Mrs. Patricia Augier and Mrs. Marion Dovis
- ITCEQ: Mrs Mounira Bouali, Mrs. Manel Gaaloul, Mr. Abdallah
Abdelmalek & Mr. Slaheddine Ammar
The findings and opinions expressed in this report are the sole
responsibility of the authors and should not be cited without permission.
They do not necessarily reflect the views of ITCEQ or AfDB.
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Table of Contents
7 Executive Summary
7 1. Introduction
9 2. Analysis by Component
9 2.1 Sector Mondeling of Manufacturing Industries
9 2.1.1 Estimation Method
9 2.1.2 Key Outputs
11 2.1.3 Employment Response to a Demand and Cost Shock
13 2.1.4 Capital Response to a Demand and Cost Shock
15 2.1.5 Conclusions
15 2.1.6 Bibliography
15 2.2 Sector Mondeling of Tunisian Eport’s Market Shares
16 2.2.1 Estimation of Export Functions Over the Period 1988-2008
25 2.2.2 Dynamic Panel Data Estimation of Export Equations
27 2.2.3 Possible Extensions of Econometric Analysis
30 2.2.4 Bibliography
30 2.3 Analysis of Demand for Tunisia’s Exports
30 2.3.1 Analysis of Tunisia’s Supply in terms of Comparative Advantage
32 2.3.2 Global Demand Trend for Tunisian Exports
37 2.4 Impacts of Opening up Tunisia’s Economy on the Productive System and Analysis of the Business Adaptation Process
38 2.4.1 Descriptive Analysis of Tunisia’s Industrial Business Database
46 2.4.2 Productivity Decomposition Analysis
50 3. Training
50 3.1 Example of Econometric and Macroeconnomic Modeling Training Session
51 3.2 Exemple of Training on Business Data Processing
54 4. Conclusions
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Executive Summary
1. Introduction
The revolution disrupted the institutional framework of the Tunisian
economy. Changes in governance and transparency in public
policies will improve the efficiency of the economy, particularly the
potential growth rate. Nevertheless, the structural characteristics
of the economy and the challenges it faces remain topical.
Due to the very high concentration of textiles and apparel exports,
the dismantling of the Multi-fibre Agreement (MFA) was a major
event for the Tunisian economy. Since the collapse of MFA, Tunisia
has faced fierce competition on EU markets from Asia and Eastern
Europe, with lower labour costs and/or higher productivity. The risk
of a structural crisis in this sector is especially high, given the degree
of dependence vis-à-vis the EU which absorbs 96% of textiles and
apparel exports from Tunisia. Furthermore, most of these exports
come from outsourcing, a vulnerable low- value-added business
activity.
However, there are some bright spots in the current structure of
manufactured exports. There are a number of new, fast-growing
export commodities, such as cable assemblies, electronic components,
plastics, essential oils and detergents. Their export share is, however,
very minimal.
Improvement of competitiveness is at the heart of a development
project based on integration into the global economy. Beyond
the indispensable modernization of technological processes, the
functioning of the labour market and specifically the wage bargaining
process, de facto initiated and supervised by the State, is not
sufficiently flexible to respond to competition from other emerging
countries on major markets. Failing to tailor the training system to the
Tunisian production model, and consequently to the demand from
businesses, hinders the improvement of competitiveness.
The share of services in value added is growing. The liberalization
of services offering speedy export opportunities should primarily
focus on promising and innovative sectors with high value added
such as IT services, engineering, accounting, auditing and
management consulting, publishing and editing, educational
services, management of public services and health services. The
implementation of these reforms would, in the medium term,
significantlyreduce Tunisia's vulnerability to fluctuations in demand
for tourism services.
Another pillar of the Tunisian development model is the growth of
FDI, which contributes to financing the needs of the economy,
despite its adverse effects on the current account (income transfers
abroad), and participates in the rapid increase in the rate of
investment.
Numerous analyses and discussions have been initiated to meet
the challenges facing the Tunisian economy. Competitiveness,
dynamics of the manufacturing sector, impact of external shocks,
role of government in an economy open to the outside world and
a better understanding of potential GDP underpin the programme
of the Technical Assistance Mission. Naturally, such a short-term
mission could not presumably address all these issues. DEFI and
ITCEQ experts have endeavoured to delimit the scope of objectives
and activities to be developed under the project, given the duration of
the mission, contingent events, and the availability of information
necessary for the completion of the programme.
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It is against such backdrop that the DEFI/ITCEQ Technical Assis-
tance mission should be repositioned. Indeed, the programme ad-
dresses, without dealing with them exhaustively, the recurrent
issues facing the Tunisian economy such as productivity of factors,
export competitiveness and substitution determinants between
non-graduates and graduates on the labour market.
The Tunisian Institute of Competitiveness and Quantitative Studies
(ITCEQ) is a public non-administrative establishment under the
supervisory authority of the Tunisian Ministry of Development and
International Cooperation. It plays a key role in planning and
programming the economic policy of the Government of Tunisia, as
well as conducting analyses necessary for public decision-making.
Within the context of Tunisia's integration into the global economy,
ITCEQ sought to strengthen its technical capacity with respect to
analyses required for public decision-making and to contribute to
the economic policy decisions of the Tunisian Government.
DEFI (Economic Development and International Finance Research
Centre) of the University of the Mediterranean (Université de la
Méditerranée), specialized in analysing the mechanisms for the
integration of emerging countries into the world economy, was
requested to implement a technical assistance mission under the
aegis of the ADB, in close conjunction with ITCEQ researchers,
whose goals, methods and findings are the subject of this
report.
1 After taking into account all the net financial flows, excluding post-crisis remittances and official loans.2 Assuming a contribution of USD 900 million under this programme (WB, AfDB, EU, AFD).
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2. Analysis by Component
2.1 Sector Modelling of Manufacturing Industries
The modelling of manufacturing industries rests on theoretical
foundations, developed in the appendices and structured
after general equilibrium models by incorporating therein elements
of demand. The objectives of modelling are to:
- Simulate and forecast the value-added growth rate of
manufacturing sub-sectors based on structural equations;
- Estimate the demand for capital input, labour for each sub-
sector;
- Estimate the elasticity of factor substitution and, for the labour
factor, the elasticity of substitution between skilled and unskilled
labour;
- Determine the price of value-added in the manufacturing sector;
- Distribute supply and demand between the domestic market
and foreign markets; and
- Provide the factor (employment and investment) demand
response to a demand (growth in value-added) and cost (salary)
shock.
The estimation period spans from 1983 to 2009. Data was collected
from the annual national accounts for the Tunisian economy. Six
manufacturing sectors are analysed, namely:
Sector 2: Agricultural and Food Industry (IAA);
Sector 3: Ceramic Building Materials and Glass Industries
(MCCV);
Sector 4: Mechanical and Electrical Industries (EMI);
Sector 5: Chemical Industries (CHEMI);
Sector 6: Textile Apparel and Leather Industries (THC); and
Sector 7: Miscellaneous Industries (MISCEL).
2.1.1. Estimation Method
The low number of observations available (at most 27) and the presence
of common parameters to be estimated in the various long-term
equations (elasticities of substitution, the growth rate of technological
progress) prompted the simultaneous estimation of these equations.
Consequently, the following two-stage process was adopted:
1. In stage one, long-term relationships were estimated, per level,
through a simultaneous equations system using the SUR
(Seemingly Unrelated Regression) method.
2. In stage two, 4 ECMs (Error Correction Models) were estimated
by imposing therein relations estimated in stage one as
long-term solution.
All ECMs have satisfactory statistical properties. LM tests result in
the rejection of the hypothesis of autocorrelation in the residuals of
these equations. These residuals are homoskedastic under the White
test and the ARCH test. The functional form of the equation passed
the Reset test. Lastly, according to the Jarque Bera test, the residuals
of all equations are normally distributed.
2.1.2. Key Outputs
The key outputs are summarized in Table 1: The following conclusions
ensue:
• There would be a relatively high substitutability between capital
and labour in 4 sectors: the elasticity of substitution is close to
unity in the Agri-food industry (IAA) as well as in the Mechanical
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and Electrical industry (EMI) (sectors 2 and 4). The elasticity of
substitution is close to 0.7 in the Ceramic Building Materials and
Glass and Chemicals industries (sectors 3 and 5). However, it is
worth noting that the value of these elasticities is probably over-
estimated by including working hours in labour. In other words,
this does not involve elasticity between capital and labour, which
is being estimated here, but between capital and work hours.
In other words, an increase in the relative price of wages
compared to the cost of capital would lead to high substitution
of capital for labour in the IAA and EMI. However, in other sectors,
the change in the relative price in both sectors has a lower but
significant incidence on the respective demand for labour and
capital in both sectors.
• However, there seems to be a strong complementarity between
capital and labour in the last 2 sectors under review, namely
Textile, Apparel and Leather and miscellaneous industries (sectors
6 and 7). This implies that in these sectors, and unlike the previous
ones, a variation in the relative cost of labour relative to capital
will have little long-term impact on capital intensity (capital stock
per worker).
• As per our estimates, it seems that the formulation of a Hicks-3
neutral technological progress is the only one to be accepted in
the six sectors studied. In sectors 2, 6 and 7, the estimated
growth rate of technical progress (gk and gl parameters, which
are identical in the Hicks-neutral technology parameters) is
between 1 and 2% per year. It is close to 2.7% in sector 4 and
above 5% in sectors 3 and 5.
The growth rate of global factor productivity is heterogeneous. It is
relatively low in IAA and textiles and high in EMI and the chemical
industry.
• In all the sectors studied, there is a high elasticity of substitution
between skilled and unskilled employment ranging from 3.3 for
sector 5 to more than 6 for sector 4. This outcome is significant,
apparently robust and relatively unexpected: It implies in particular
that a 1% decrease in the relative wage of skilled workers versus
unskilled workers would lead (in the long run) to an increase in
the number of jobs for skilled workers higher than that of unskilled
workers by 3% to 6%. In other words, a tighter wage gap
between skilled and unskilled workers would be, according to
this estimate, an effective means of improving the "employability"
of graduates. One possible interpretation of this result is that,
on average, graduates would not have enough specific expertise
that would suitably distinguish them from unskilled workers, given
that both categories are consequently considered by businesses
as substitutes rather than complements in the production
process.
• In conclusion, it should be recalled that long-term elasticities
with respect to quantities were fixed to unity, for obvious reasons
of theoretical consistency: thus, when the total amount of work
increases by 1%, the amount of hours put in by skilled and
unskilled workers increases identically by 1% (all things being
equal). Similarly, when demand for goods (measured by value
added in volume) increases by 1%, the amount of capital and
labour increases identically by 1%.
3 Technological progress is Hicks-neutral if it increases the effectiveness of both factors of production. For a given productive combination, the ratio of marginal productivitiesremains unchanged and the demand for factors increases to keep pace with technical progress.4 It should be noted that the distinction between skilled/unskilled workers here is understood in terms of degree and not the type of business: in our estimates, skilled workerswere defined as higher education graduates, while the unskilled comprise other individuals. The terms used in our presentation ("skilled workers" and "unskilled workers") aretherefore deliberately simplistic and highly schematic. To complete the estimation, long-term equations were placed in the broader context of error correction models. The genericform of the dynamic equations estimated is given in Table III.4. As above, the non-significant short-term coefficients were removed from the final equations.
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To illustrate the dynamic process of the different variables and their
sensitivity to economic determinants, the assessment of sector
responses to some economic shocks was conducted.
2.1.3. Employment Response to Demand and Cost Shock
Two shocks were simulated: the first is a 1% increase in value added,
whereas the second shock is a 1% increase in real wages.
The outcomes of these simulations are summarized in Table 2 and
in the graphs below. Responses to shocks reveal that in the wake
of a shock, employment does not recover its initial value. In the
case of a demand shock (VA), the employment response is fastest
in the MCCV, EMI and THC sectors. The shocks are still very
persistent 4 years later. Following an increase in real wages, the
adverse effects on employment are felt instantly in the IAA and to
a lesser extent in EMI and the chemicals industry. In the long run,
the IAA and EMI are the sectors whose jobs are the most affected.
In contrast, employment in the textile sector seems to better absorb
the shock and be relatively preserved in the long run.
Table 1: Trend of Economic Indicators (2008-2011)
Sources: National Accounting, ITCEQ/DEFI calculations
Sector 2 3 4 5 6 5
Structural Parameters
Elasticity of substitution K/L 0.99 0.74 0.98 0.67 0.06 0.14
Elasticity of substitution Skilled/Unskilled labour
5.40 4.10 6.01 3.29 4.67 5.55
Hicks-Neutral technical progress(%)
1.97 5.11 2.68 5.28 1.06 1.67
ECM Parameters
Employment buoyancy 0.40 0.21 0.32 0.12 0.21 0.31
Capital buoyancy 0.05 0.13 0.07 0.06 0.14 0.04
Table 2: Dynamic Response of a 1% VA and Real Wages (RW) Shock on Employment)
Sources: National Accounting, ITCEQ/DEFI calculations
Sector T 1 year 2 years 3 years 4 years Long term
IAA (2)VA 0.31 0.46 0.62 0.71 0.79 1
RW -1.16 -0.63 -0.97 -0.84 -0.94 -0.98
MCCV(3)VA 0.85 0.88 0.38 0.52 0.62 1
RW 0 -0.77 -0.76 -0.75 0.74 -0.73
IME(4)VA 0.44 0.62 0.74 0.82 0.88 1
RW -0.21 -0.46 -0.62 -0.73 -0.81 -0.97
CHEMI (5)VA 0.19 0.30 0.28 0.31 0.32 1
RW -0.22 -0.06 -0.01 -0.20 -0.28 -0.67
THC(6)VA 0.37 0.50 0.61 0.69 0.76 1
RW -0.47 -0.38 -0.31 -0.26 -0.21 -0.05
MISCEL. (7)VA 0.53 0.68 0.78 0.85 0.90 1
RW 0 -0.04 -0.07 -0,09 -0.11 -0.13
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Graph 1: Employment variation (in %) following a 1% increase in value added
Graph 2: Employment variation (in %) following a 1% increase in real wages
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2.1.4. Capital Response to Demand and Cost Shock
Two shocks were also simulated for capital:
1. A 1% increase in value added
2. A 1% increase in the real cost of capital
The results of these simulations are summarized in Table 3 and in
the graphs below. Responses to capital shocks show a large enough
inertia in the short term in most sectors, except textiles, for value
added. In contrast, the long-term effects of an increase in the real
cost of capital5 are substantial in IAA, IME, and MCCV, but negligible
in the textile and apparel sector.
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Table 3: Dynamic Response of a 1% VA Shock and Actual Cost (CKR) on Capital Stock
Sources: National Accounting, ITCEQ/DEFI calculations
Sector T 1 year 2 years 3 years 4 years Long term
IAA
VA 0.18 0.51 0.71 0.83 0.91 1
RW -0.10 0.27 -0.40 -0.50 -0.64 -0.98
MCCV
VA 0.17 0.36 0.58 0.78 0.93 1
RW -0.14 -0.29 -0.45 -0.61 0.73 -0.73
IME
VA 0 0.18 0.42 0.65 0.83 1
RW 0 -0.07 -0.21 -0.39 -0.56 -0.97
CHEMI
VA 0 0.15 0.25 0.39 0.52 1
RW -0.03 -0.15 -0.24 -0.34 -0.43 -0.67
THC
VA 0.27 0.50 0.67 0.79 0.87 1
RW -0.008 -0.028 -0.036 0.042 -0.047 -0.05
MISCEL.
VA 0 0.04 0.10 0.17 0.24 1
RW -0.04 -0.07 -0.08 -0,09 -0.10 -0.13
5 Real cost of capital: the real interest rate plus the rate of capital depreciation.
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Graph 3: Capital stock variation (in %) following a 1% increase in value added
40
Graph 4: Employment variation (in %) following a 1 % increase in actual cost
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2.1.5. Conclusions
The modelling of micro-manufacturing sectors, based on approaches
to computable general equilibrium models, has given rise to estimates
of parameters leading to the following conclusions:
- The substitution between capital and labour is high (elasticity
close to unity, Cobb-Douglas) in the Food and Agricultural Industry
as well as in the Mechanical and Electrical Industries (sectors 2
and 4), both of which are strong exporters. Substitution between
both factors is weaker (elasticity close to 0.7, CES) in the MCCV
and Chemicals sectors. In other sectors, there is complementarity
between production factors;
- Dynamic simulations reveal that Tunisia's industrial sectors are
characterized by a relatively high rigidity with respect to the
adjustment of factors: in the wake of demand or actual cost
shocks, it generally takes three to four years for a significant
adjustment to occur in the quantity of labour and capital;
- The global productivity growth rate of factors is heterogeneous.
It is relatively low in IAA and textiles, and high in EMI and the
chemicals industry;
- In all the sectors studied, there is a high elasticity of substitution
between skilled and unskilled employment6 ranging from 3.3 for
sector 5 to more than 6 for sector 4. This outcome is significant,
apparently robust and relatively unexpected: It implies in particular
that a 1% decrease in the relative wage of skilled workers versus
unskilled workers would lead (in the long run) to an increase in
the number of jobs for skilled workers higher than that of unskilled
workers by 3% to 6%.
Consequently, these initial findings allow for the validation of both
the theoretical and econometric methodologies implemented. Hence,
based on the work done in this study, sector estimates of prices and
foreign trade - which still have to be done - must be conducted
without major difficulties.
2.1.6. Bibliography
Annabi N., Cockburn J., Decaluwé B. (2003), Formes
Fonctionnelles et Paramétrisation dans les MCEG, CREFA,
Université de Laval
Harrison R., Nikolov K., Quinn M., Ramsay G., Scott A. and
Thomas R. (2005), The Bank of England Quarterly Model,
www.bankofengland.co.uk/publications/beqm/
Klump R., McAdam P., Willman A. (2008), Unwrapping some euro
area growth puzzles: Factor substitution, productivity and
unemployment. Journal of Macroeconomics 30, 645–666
Lofgren H., Harris R.L., Robinson S. (2002), A standard computable
general equilibrium model in GAMS. Microcomputer in Policy
Research 5, International Food Policy Research Institute.
2.2 Sector Modelling of Tunisian Exports MarketShares
The analysis of the determinants of Tunisia's exports covers eight
sectors identified by ITCEQ experts, as follows:
Sector 1: Agriculture (Agr)
Sector 2: Agri-food Industry (IAA)
Sector 3: Ceramic Building Materials and Glass (MCCV)
Sector 4: Mechanical and Electrical Industries (IME)
Sector 5: Chemical Industries (CHEMI)
Sector 6: Textile, Apparel and Leather Industries (THC)
6 It should be noted that the distinction between skilled/unskilled workers here is understood in terms of degree and not the type of business: in our estimates, skilled workerswere defined as higher education graduates, while the unskilled comprise other individuals. The terms used in our presentation ("skilled workers" and "unskilled workers") aretherefore deliberately simplistic and highly schematic.
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Sector 7: Miscellaneous Industries (MISCEL)
Sector 8: Hydrocarbons (Hyd)
The objective is to conduct a quantitative assessment of sector
exports dynamics as a result of variations in expressed demand and
relative prices.
Under the project, implementation is limited to the study of Tunisia's
exports toward Europe, which represents the bulk of its exports,
based on annual data covering the period 1988-2008.
i) The explanatory variables of Europe’s7 import demand are:
- European expressed demand;
- Tunisian sector export price index;
- European price index; and
- Tunisia's competitor price index on the European market.
ii) The theoretical modelling included in the Annex is an extension
of conventional export models8.
iii) The estimation of econometric equations is based on the
specification of error-correction models. This approach has the
advantage of distinguishing between short-term elasticities and
long-term elasticities of European sector imports.
iv) This methodology is supplemented by dynamic panel estimates
where the sample size is much larger and therefore allows for
the testing of the robustness of the results of time series data
comprising 21 observations covering the period 1988-2008.
v) In addition, some interesting extensions in terms of modelling,
that can be undertaken as a continuation of existing work, are
suggested and initiated:
- First, econometric estimates may be supplemented by a sector
model for the modelling of prices and quantities (imports and
exports), leading to the assessment of nominal flows and trade
balances by sector;
- Second, modelling may introduce nonlinearities. These take into
account the possibility of time-varying elasticity. For example,
price elasticities may be lower when price differentials are small
and more significant when the price differentials increase, due
to the existence of transaction costs; and
2.2.1. Estimation of export functions on time series datacovering the period 1988-2008
2.2.2.1. The theoretical modelling reported in the Annex proposes
three potential explanatory variables for Tunisian exports:
- European expressed demand;
- Price index of Tunisian sector export models;
- European price index; and
- Tunisia's competitor price index on the European market.
However, preliminary estimates of export functions by sector
revealed collinearity problems between different price indexes that
made it difficult to interpret the estimated coefficients. Therefore,
the following dynamic specification was retained, which is restricted
to the consideration of only one relative price (p) which, as stated
below, may take two different specifications:
(1) Δx(t) = ρΔx(t-1) + α0Δd(t) + α1Δd(t-1) + α2 Δd(t-2) + φ0Δp(t)
+ φ1Δp(t-1) + φ2Δp(t-2)
+ γ [ x(t-1) - βp(t-1) – d(t-1) + μ.t ] + εt
x: logarithm of Tunisian exports to the European Union (EU) in
thousand Euros constant base 100 = 2005 (compiled from Comext).
7 See for example Annabi N., Cockburn J., Decaluwé B. (2003) for a presentation on the microeconomic foundations of demand functions.8 See for example Wong (2008) for a recent application to the case of Malaysia.
17
d: logarithm of the demand made to Tunisia by the EU at constant
prices (compiled from Comext). The demand will be expressed in 2
alternative ways:
- The first considers demand expressed for all commodities in the
sector concerned (Agriculture, IAA, ...)
- The second limits the demand to Tunisia's main exports in a
given sector (Agriculture, IAA,). Indeed, there is considerable
heterogeneity in the composition of commodities from each
sector, and in this form, expressed demand may be the more
representative model for Tunisian exports.
p: logarithm of the relative price of Tunisian exports. This relative
price is expressed in 2 alternative ways:
- The first one retains an index of sector relative prices for Tunisian
exports with respect to EU imports in the same sector;
- The second uses an index of relative prices for Tunisian exports
with respect to those of major competitors on the European market.
Hence, for each sector, 4 formulations were estimated according to
whether expressed demand should be calculated on all commodities
or restricted to the major export, and whether the relative price
should be calculated based on competitor prices or that of European
Union countries.
In this error-correction model (ECM), the term in brackets [ x(t-1) - βp(t-
1) – d(t-1)] represents the deviation from long-term equilibrium, wherein
long-run elasticities are equal to 1 with respect to expressed demand
(in fact, Tunisia’s market share trend is modelled on the European
market) and from β with respect to the relative price.
The term μ.t stands for the potential deterministic trend of market
shares, with an annual growth rate μ.
Lastly, the variables Δx represent the variation of x, and
dummy variables were sometimes included in the regression
model.
2.2.2.2. Key Outputs
1) Agriculture
The main findings, for the 4 specifications tested for this sector,
are summarized in Table 4:
• The value of the long-run elasticity of demand for exports was
imposed to unity. It is worth noting that, in preliminary tests, this
restriction is more easily accepted by using expressed demand
calculated on the basis of major commodities;
• Whenever expressed demand for "Total exports" is used, our
estimates reveal a significantly positive trend, representing an
increase in market shares trend for this sector;
• Long-term price elasticities bear the expected sign in three out
of four cases. Only the formulation with EU prices and "major
exports" for demand bears a positive sign, contrary to economic
intuition. The value of this elasticity is low, to the tune of-.2 in
the case of competitor prices and -0.3 in that of EU countries,
which would imply that Tunisian products in the sector have few
substitutes on the EU import market; and
• ECMs that use "Total commodities" for demand have satisfactory
statistical properties. LM tests result in the rejection of the
hypothesis of autocorrelation in the residuals of these equations.
These residuals are homoskedastic under the White test and
the ARCH test. The functional form of the equation passed the
Reset test. Lastly, according to the Jarque Bera test, the residuals
of all equations are normally distributed. That is not the case for
hose using "Major exports" for demand.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
18
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 4: Summary of Key Findings of the Export Equation Estimates for Sector 1
Source: ITCEQ/DEFI Calculations / Note: Student's t-statistic is shown in bracketsne: coefficient was not estimated but imposed.
α0 Total Commodities Major Commodities
Expressed Demand 1ne 1ne 1ne 1ne
Buoyancy -0.63 (-3.70) -0.31 (-1.45) -0.38 (-2.21) -0.65 (-3.28) γ
Relative Prices of …… competitors -0.20 (-0.28) -0.17 (-1.00) β
… EU as a whole -0.30 (-2.09) 0.06 (0.12)
Trend 0.007 (2.12) 0.02 (1.81) μ
ST ElasticitiesΔlog(expressed demand) 1.49 (3.57) α0Dummyd98 0.16** (1.91) 0.16* (2.03) η0d06 0.23 (2.32) η1d02 -0.14 (-1.72) η2TestsLM (2) 0.82 0.21 0.03 0.10
Arch(1) 0.72 0.33 0.72 0.33
Normality 0.71 0.56 0.92 0.38
Reset (2) 0.97 0.29 0.08 0.05
R-squared 0.63 0.50 0.44 0.39
Adjusted R-squared 0.46 0.32 0.34 0.33
Ranking 1 4 3 2
At the end of these estimates, it seems the best equation is one that
uses "Total exports" as expressed demand and considers the prices
of EU countries as foreign price.
2) IAA Sector
• The value of elasticity of demand for exports was imposed to
unity. It is worth noting that this restriction is accepted in all
cases;
• Long-term price elasticities have the expected sign in three
out of four cases. Only the formulation with the price of EU
countries and "major exports" for demand bears a positive
sign, contrary to economic intuition. The value of this elasticity
is -0.7 in the case of competitor prices and -0.5 in that of EU
countries; and
• All ECMs have satisfactory statistical properties. LM tests result
in the rejection of the hypothesis of autocorrelation in the
residuals of these equations. These residuals are homoskedastic
under the White test and the ARCH test. The functional form of
the equation passed the Reset test. Lastly, according to the
Jarque Bera test, the residuals of all equations are normally
distributed.
According to these estimates, the best equation is the one that uses
"Total exports" for demand and considers the prices of EU countries
as foreign price. Findings are summarized in the table below.
19
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 5: Summary of Key Findings of the Export Equation Estimates for Sector 2 Estimation (Period: 1988-2008)
Source: ITCEQ/DEFI Calculations / Note: Student's t-statistic is shown in bracketsne: coefficient was not estimated but imposed.
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy -1.13 (-6.10) -1.19 (-5.82) -1.19 (-9.94) -1.33 (-5.99)γ
Relative Prices of …
… competitors -0.64 (-1.87) -0.74 (-2.39)β
… EU as a whole -0.54 (-1.61) 0.26 (2.47)
Trend μ
ST Elasticities
Δ( Relative prices)-0.89 (-2.61) -0.93 (-2.54) -0.75* (-2.06)
φ0
Dummy
d02 -0.93 (-3.52) -0.87 (-3.25) -0.98 (-3.97) -1.12 (-4.11)η0
d01 -0.96 (-3.10) -0.90 (-2.74) -0.93 (-3.13) -1.15 (-3.32)η1
d96 -0.79 (-3.32)η2
d94 0.48* (2.09) 0.62 (3.74)η3
Tests
LM (2) 0.55 0.32 0.37 0.87
Arch(1) 0.85 0.70 0.33 0.93
Normality 0.80 0.86 0.83 0.74
Reset (2) 0.10 0.52 0.12 0.76
R-squared 0.87 0.81 0.86 0.82
Adjusted R-squared 0.80 0.75 0.80 0.76
Ranking 1 3 4 2
3) Ceramic Building Materials and Glass Sector (MCCV)
• The value of elasticity of exports demand was imposed to unity.
It is worth noting that this restriction is accepted econometrically
in the case of "Total commodities". The elasticity in the case
of "Major exports" is close to 0.6 when the coefficient is
left free.
• Long-term price elasticities bear the expected sign in all cases.
he value of this elasticity is close to -0.5, indicating a significant
price effect.
• ECMs that use "Total exports" for demand have satisfactory
statistical properties. LM tests result in the rejection of the hypothesis
of autocorrelation in the residuals of these equations. These
residuals are homoskedastic under the White test and the ARCH
test. The functional form of the equation passed the Reset test.
Lastly, according to the Jarque Bera test, the residuals of all
equations are normally distributed. That is not the case for those
using "Major exports" for demand.
20
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 6: Summary of Key Findings of the Export Equation Estimates for Sector 3 (Period: 1988-2008)
Source: ITCEQ/DEFI Calculations / Note: Student's t-statistic is shown in bracketsne: coefficient was not estimated but imposed.
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy -0.88 (-6.66) -0.87 (-6.63) -0.74 (-4.70) -0.73 (-4.92) γ
Relative Prices of …
… competitors -0.46 (-3.81) -0.57 (-3.21) β
… EU as a whole -0.44 (-3.64) -0.49 (-2.69)
Trend μ
ST Elasticities
Dummy
d9293 -0.52 (-2.86) -0.51 (-2.84) -0.68 (-2.78) -0.63 (-2.76) η0
Tests
LM (2) 0.52 0.70 0.49 0.61
Arch(1) 0.35 0.41 0.58 0.75
Normality 0.63 0.68 0.26 0.23
Reset (2) 0.37 0.23 0.01 0.01
R-squared 0.85 0.86 0.76 0.79
Adjusted R-squared 0.83 0.83 0.72 0.75
Ranking 1bis 1 3bis 3
4) Mechanical and Electrical Industries Sector
• The value of elasticity of demand for exports was imposed to
unity. Unstressed, such elasticity would exceed unity, reaching
around 1.3 in both cases.
• In all ECMs, estimates reveal a significantly positive trend,
signifying an increased market share trend in this sector. This
is consistent with elasticity of expressed demand exceeding
unity.
• Long-term price elasticities do not have the expected sign when
competitor prices are included in the relative price. In the other
case, the estimated elasticity is relatively high, between -
1 and -1.5.
• All ECMs have satisfactory statistical properties. LM tests result
in the rejection of the hypothesis of autocorrelation in the
residuals of these equations. These residuals are homoskedastic
under the White test and the ARCH test. The functional form
of the equation passed the Reset test. Lastly, according to the
Jarque Bera test, the residuals of all equations are normally
distributed.
This sector over-reacts to the European economic situation and
is also very competitive.
21
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Source: ITCEQ/DEFI Calculations / Note: Student's t-statistic is shown in bracketsne: coefficient was not estimated but imposed.
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy -0.22 (-2.31) -0.13 (-2.27) -0.66 (-8.86) -0.73 (-2.71) γ
Relative Prices of …
… competitors 0.09 0.27 β
… EU as a whole -1.10 -1.56
Trend 0.09 0.08 0.10 0.06 μ
ST Elasticities
Δlog(Expressed Demand) 0.42 (4.36) 0.35 (2.92) 0.72 (8.91) α0
Δ( Relative Prices) -0.32 (-2.77) -0.14 (-1.24) -0.53 (-6.24) φ0
Δ( Relative Prices) -1 0.39 (4.12) φ1
Δlog(Exports)-2 -0.28 (-4.91) ρ0
Dummy
d89 0.14 (3.60) 0.12 (2.48) η0
d06 0.16 (3.28) 0.17 (2.70) 0.10 (7.65) η1
d96 -0.18 (-3.68) η2
Tests
LM (2) 0.34 0.54 0.36 0.61
Arch(1) 0.72 0.86 0.16 0.32
Normality 0.67 0.34 0.72 0.35
Reset (2) 0.64 0.40 0.83 0.35
R-squared 0.83 0.75 0.98 0.63
Adjusted R-squared 0.73 0.61 0.96 0.53
Ranking 1bis 3 1 3bis
Table 7: Summary of Key Findings of the Export Equation Estimates for Sector 4 (Period: 1988-2008)
The best equation is the one that uses the prices of all EU coun-
tries in the competitiveness indicator, and for major commodities
only.
5) Chemical Sector
• The value of elasticity of demand for exports was imposed to
unity. Unstressed, such elasticity would exceed unity, reaching
around 1.5 in all cases, except for case 4 (expressed demand,
“major commodities”, competitor prices), where elasticity stands
at 0.8;
• In all ECMs, estimates reveal a significantly negative trend,
signifying a loss-of-market share trend in this sector. This is
consistent with elasticity of demand below unity;
• Price elasticities bear the expected sign, regardless of the
formulation used, although their value varies greatly: it stands
around -0.7 / -0.9 in the case of a "Total commodities" demand.
These values become much higher (-1.89 and -4.67 respectively)
when expressed demand includes "Major commodities". This
indicates a high degree of substitutability of Tunisia's chemical
exports with respect to competing exports;
• All ECMs have satisfactory statistical properties. LM tests result
in the rejection of the hypothesis of autocorrelation in the
residuals of these equations. These residuals are homoskedastic
under the White test and the ARCH test. Lastly, according to
the Jarque Bera test, the residuals of all equations are normally
distributed. The functional form of the equation alone failed the
Reset test.
22
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 8: Summary of Key Findings of the Export Equation Estimates for Sector 4 (Period: 1988-2008)
Source: ITCEQ/DEFI Calculations / Note: Student's t-statistic is shown in bracketsne: coefficient was not estimated but imposed.
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy -0.75 (-2.70) -0.67 (-2.36) -0.23 (-1.99) -0.39 (-3.55) γ
Relative Prices of …
… competitors -0.88 (-2.35) -4.67 (-3.91) β
… EU as a whole -0.70 (-2.69) -1.89 (-2.09)
Trend -0.06 (-3.40) -0.06 (-3.19) -0.11 (-2.63) -0.13 (-4.47) μ
ST Elasticities
Δlog(Expressed Demand) α0
Δ( Relative Prices) -0.15 ** (-1.79) α1
Δ( Relative Prices) -1 1.52 (2.90) φ1
Δlog(Exports)-2 1.39 3.00) ρ2
Dummy
d9394 -0.18* (-2.26) -0.19 * (-2.28) -0.24 (-2.69) -0.28 (-4.08) η0
Tests
LM (2) 0.75 0.42 0.73 0.19
Arch(1) 0.49 0.91 0.37 0.30
Normality 0.63 0.68 0.61 0.42
Reset (2) 0.07 0.10 0.07 0.02
R-squared 0.74 0.73 0.65 0.86
Adjusted R-squared 0.62 0.60 0.53 0.74
According to these estimates, it would seem the best equation is
one that uses prices calculated based on competitor prices in the
competitiveness indicator and "Major exports" for demand.
6) Textile, Apparel and Leather Sector
• The value of elasticity of demand for exports was imposed to
unity. Such unstressed elasticity would fall below unity, and
stand at about 0.6 in all cases;
• Price elasticities bear the expected sign, regardless of the
formulation used, and their value is high, stabilized between -
3 and -4 when competitors’ prices are used and between -
5 and -8 in the other case. Consequently, as in the case of
chemical industries, there would be a phenomenon of high
substitutability of these exports on the European market.
• All ECMs have satisfactory statistical properties. LM tests result
in the rejection of the hypothesis of autocorrelation in the
residuals of these equations. These residuals are homoskedastic
under the White test and the ARCH test. The functional form
of the equation passed the Reset test. Lastly, according to the
Jarque Bera test, the residuals of all equations are normally
distributed.
23
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 9: Summary of Key Findings of the Export Equation Estimates for Sector 6 (Period: 1988-2008)
Source: ITCEQ/DEFI Calculations / Note: Student's t-statistic is shown in bracketsne: coefficient was not estimated but imposed.
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy -0.14 (-2.12) -0.15 (-3.31) -0.10 (-2.21) -0.15 (-3.56) γ
Relative Prices of …
… competitors - 2.88 (-9.01) -4.21 (-8.27) β
… EU as a whole -5.30 (-4.99) -8.04 (-6.39)
Trend μ
ST Elasticities
Δ( Relative Prices) -0.26 (-2.33) φ0
Dummy
d01 0.16 (2.41) 0.15 (2.25) 0.19 (2.73) η0
Tests
LM (2) 0.84 0.48 0.62 0.46
Arch(1) 0.36 0.69 0.62 0.88
Normality 0.69 0.98 0.64 0.58
Reset (2) 0.16 0.89 0.77 0.77
R-squared 0.65 0.84 0.80 0.86
Adjusted R-squared 0.55 0.81 0.76 0.82
Ranking 4 2 3 1
According to these estimates, the best equation is one that uses
prices calculated based on competitor prices in the competitiveness
indicator and "Major exports" as demand.
7) Hydrocarbons and Refined Products Sector
• The value of elasticity of demand for exports was imposed to
unity. It is worth noting that this restriction is more easily accepted
when using expressed demand calculated on the basis of “Total
commodities” (estimated elasticity is1.03) than in the case of
“Major commodities” (elasticity estimated above 0.8);
• Price elasticities always have the expected sign. The value
ranges between -8 in the case of EU prices and around -5 in
the case of competitor prices. This sector is characterized by
the highest price elasticities among the sectors studied. This
is not surprising, given the type of products involved in the
sector: hydrocarbons are standardized exports, and Tunisian
commodities are close substitutes with respect to exports traded
on the European market.
• All ECMs have satisfactory statistical properties. LM tests result
in the rejection of the hypothesis of autocorrelation in the
residuals of these equations. These residuals are homoskedastic
under the White test and the ARCH test. The functional form
of the equation passed the Reset test. Lastly, according to the
Jarque Bera test, the residuals of all equations are normally
distributed.
24
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 10: Summary of Key Findings of the Export Equation Estimates for Sector 8 (Period: 1988-2008)
Source: ITCEQ/DEFI Calculations / Note: Student's t-statistic is shown in bracketsne: coefficient was not estimated but imposed.
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy -0.83 (-6.31) -0.41 (-2.31) -0.66 (-3.75) -0.38 (-2.02) γ
Relative Prices of …
… competitors -5.65 (-1.69) -4.47 (-1.29) β
… EU as a whole -7.93 -7.93 (-3.81)
Trend μ
ST Elasticities
Dummy
d9394 -0.53 (-4.52) -0.68 (-3.60) -0.65 (-5.09) -0.71 (-3.74) η0
Tests
LM (2) 0.11 0.26 0.65 0.30
Arch(1) 0.83 0.84 0.12 0.84
Normality 0.89 0.27 0.73 0.21
Reset (2) 0.80 0.68 0.30 0.62
R-squared 0.89 0.69 0.86 0.67
Adjusted R-squared 0.87 0.63 0.82 0.61
Ranking 1 3 2 4
The best equation is that which uses “Total exports” as demand
and EU prices as foreign price.
8) Estimation of Global Equation
• The value of elasticity of demand for exports was imposed to
unity. It is worth noting that this restriction is more easily
accepted when using expressed demand calculated on the
basis of “Total commodities” (estimated elasticity is1.01) than
in the case of “Major commodities” (elasticity estimated
above 0.9);
• Price elasticities always have the expected sign except for
formulation 3 (prices of all EU countries and expressed demand
(Major commodities). The value ranges between -0.3 and -0.5
in the other cases;
• All ECMs have satisfactory statistical properties. LM tests result
in the rejection of the hypothesis of autocorrelation in the
residuals of these equations. These residuals are homoskedastic
under the White test and the ARCH test. The functional form of
the equation passed the Reset test. Lastly, according to theJarque
Bera test, the residuals of all equations are normally distributed.
25
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 11: Summary of Key Findings of the Export Equation Estimates for Total Goods (Period: 1988-2008)
Source: ITCEQ/DEFI Calculations / Note: Student's t-statistic is shown in bracketsne: coefficient was not estimated but imposed.
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy -0.53 -0.49 -0.53 -0.57 γ
Relative Prices of …
… competitors -0.49 -0.31 β
… EU as a whole -0.53 0.35
ST Elasticities
Δlog(Expressed Demand)-1 -0.44 α1
Δ( Relative Prices)-1 -0.35 φ1
Dummy
d9394 -0.14 -0.11 -0.13 -0.12 η0
Tests
LM (2) 0.59 0.36 0.78 0.87
Arch(1) 0.55 0.86 0.51 0.43
Normality 0.73 0.96 0.20 0.42
Reset (2) 0.08 0.17 0.14 0.87
R-squared 0.78 0.83 0.75 0.82
Adjusted R-squared 0.74 0.78 0.68 0.79
Ranking 3 2 4 1
The best equation is that which uses “Total exports” as demand
and competitor prices as foreign price.
2.2.2.3. Conclusion
In conclusion, the findings of the estimates conducted provide
important lessons, as they highlight huge differences among
sectors, both with respect to the long-term price elasticities of the
various sectors (and hence their level of substitutability on the
European market), and to the dynamic behaviour of Tunisian
exports in the wake of relative price shocks and demand shocks
(see Appendix). Henceforth, the estimation of an aggregate export
equation, even if it meets econometric quality criteria, cannot
underpin forecasts and the formulation of a coherent industrial
development policy.
2.2.2. Estimation of export functions on time series datacovering the period 1988-2008
Dynamic panel estimates confirm the results obtained from time
series data.
2.2.2.1. Estimation Methods
Three econometric approaches consistent with the methods used
for time series data were developed, namely:
26
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
i) an autoregressive distributed lag (ADL) model in levels (assuming
stationarity of the series), by using two alternative specifications
for relative prices: one based on EU prices and the other based
on competitor prices on the European market;
ii) an autoregressive distributed lag (ADL) model in first differences
(assuming non-stationarity of the series), by using the two
alternative specifications for relative prices; and
iii) an error-correction model (ECM) estimated in one step, which
allows the inclusion of integrated and non-cointegrated cases,
still under the two alternative specifications for relative prices.
2.2.2.2. Key Findings
1) ADL Model in levels in the case of EU prices (LPUE)The estimated value of the elasticity of demand for exports is 0.82
and 0.27 in the long term and short term, respectively.
The estimates reveal a significantly positive trend, which represents
an increased market share trend.
Price elasticities bear the expected sign: the value of this elasticity
is -0.71 in the short term and long term.
The ADL model has satisfactory statistical properties.
2) ADL Model in levels in the case of competitor prices (LPCON)
The value of the elasticity of demand for exports is 0.83 in the long
run and 0.26 in the short run.
Our estimates reveal a significantly positive trend, signifying an
increased market share trend in this sector.
Estimated price elasticities stand at -0.65 in the short term and -
0.71 in long term.
Residuals of this equation have satisfactory statistical properties.
There is very little difference between the two specifications, one
that includes the EU prices in the relative price and the other which
uses competitor prices on the European market.
3) ADL Model in variation
Whatever the relative prices chosen, with respect to Tunisia’s
competitors or the EU countries, the short-run elasticity of demand
by the EU is not significant. In contrast, for the two specifications
(competitor prices and EU prices), price elasticities are significant,
ranging from -0.65 in the short term to -0.7 in the long-term, and
equivalent to those obtained for the model in level.
4) ECM Model in the Case of Prices of Competitor Countries
The value of the elasticity of demand for exports is 0.83 in the long
run and 0.26 in the short run.
Our estimates reveal a significantly positive trend, signifying an
increased market share trend in this sector.
Estimated price elasticities stand at -0.65 in the short term and -
0.71 in long term.
Residuals of this equation have satisfactory statistical properties.
2.2.2.3. Conclusions
In conclusion, the data panel estimates helped to meaningfully
supplement the estimates made for each sector considered separately.
Given the low number of observations in the sample studied, data
panel estimation allows for a rather robust estimation of the 'average’
dynamic behaviour of sector exports. It follows that, whatever the
specifications used for the measurement of relative prices:
i) The elasticity of Tunisian exports to Europe in relation to expressed
demand is close to unity in the long run (this unit value is not
statistically rejected in ECMs), but, on average, seems relatively
low in the short term and even non-significant in growth rate
estimates. As a result, the instantaneous effect of a variation in
expressed demand may be considered negligible, given that
sector export adjustments probably require a time frame
substantially greater than one year.
ii) The price elasticity of Tunisian exports to Europe stands at -0.6
to -0.73 both in the short and long terms.
27
iii) Lastly, the residual plots of the various models estimated suggest
that the IAA, IMCCV (the first sub-period) and hydrocarbons
sectors are the least close to the overall estimate, which justifies
the sector approach. Indeed, the time series data reveal that the
hydrocarbons sector has much higher price elasticity than other
sectors, while the IAA sector has relatively high short-term
demand elasticities compared to other export sectors.
2.2.3. Possible Extensions of Econometric Analysis
2.2.3.1. A Foreign Trade Model
All analytical forms of the various equations are developed in
documents devoted to each component. Only some of them and
underlying intuitions are included in the following paragraphs.
1) Import Volume Function
The determinants usually adopted in the volume of imports are
domestic demand, a term in competitiveness formulated as the
relative price of domestic production compared to import prices
(usually calculated, excluding energy) and a term in productive capital
utilization. Usually, the cyclical economic pressures on production
capacity are described by integrating this equation into the utilization
rates of domestic production capacity relative to those of key
partners. This ratio helps to identify a possible supply constraint
which is subject to the national economy. The expected sign of its
elasticity with respect to imports is positive: when utilization rates
are higher in Tunisia than in its main partners, the increased domestic
demand is directed towards foreign producers, thereby increasing
the volume of imports. Lastly, some models enrich the analysis by
incorporating non-price competitiveness such as effort in research
and development (for example the integration of the age of capital).
2) Export Price Function
In fixing their prices, Tunisian producers are alleged to have a margin-
driven attitude towards foreign and domestic markets alike.
Nevertheless, to cope with foreign competition, they also take
account of foreign prices when setting export prices. Hence, there
is a trade-off between the margin-driven attitude (passing on the
total fluctuations in unit cost9 to export prices, so as to maintain a
constant profit margin), and a competitiveness-driven attitude
(passing on the total fluctuations in foreign prices to export prices
in a bid to maintain competitiveness). This trade-off translates into
a long-term target expressed as a weighted average of foreign prices
and domestic costs.
3) Import Price Function
Importers conduct a trade-off similar to that of exporters: in order
to maintain profit margins, they index their selling price on Tunisian
territory to their production costs, approximated by foreign import
prices. However, in order to maintain their competitiveness in
relation to domestic products, they also take into account domestic
production prices. Unlike foreign export prices, the foreign import
price is derived from simple weighting, given that competition takes
place only on Tunisian territory and therefore does not take third-
country markets into account.
4) VAR Modelling from the Cointegration Equation
As demonstrated in the final document of Component 2.1 based
on a cointegration equation of the form:
X iT(t) = a0 y(t) + a1 [piE(t) - py(t)] + f0 [piT(t) - piE(t) ] + G. f1 [piT(t) - piE(t)
]+ c + ê(t),10 ,
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
9 An approximation of unit costs may be made by incorporating domestic production prices.10 piE ; European competitor prices for commodity i,, py : GDP prices, piT : Tunisian price for commodity i, y(t) expressed demand.
28
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
It is possible to proceed with the estimation of a VAR model, in order
to conduct forecast exercises.
However, estimating such a model for each sector is a huge task,
and it is probably possible only after a selection of the most important
sectors for analysis (or considering only Tunisian exports to Europe
as a whole).
5) Non-linearities
The long-term structural equation for exports in Section 3.2 is based
on the assumption of constant elasticities. However, various forms
of non-linearities or structural changes may be considered.
- Temporal variation in income elasticity
For example, one can consider that income elasticity depends on
the European economy: in the early stages of the economic cycle
(for example, when unemployment rate u is higher than the natural
rate û), the income elasticity may be higher than in the low phases
of the cycle (when the unemployment rate is below the natural
rate).
In order to model this process, a formalization based on nonlinear
smooth transition models (Smooth Transition) may be proposed.
- Temporal variation in price elasticity
The price elasticity of foreign trade may depend on the absolute
difference between Tunisian export prices and competitor export
prices piT(t) - piE(t).
Indeed, when the price differential is small, i.e. when [piT(t-1) - piE(t-
1)]² is close to zero (or a given threshold k), the price elasticity of
Tunisian exports may be assumed to be relatively low, whereas when
the price differential is huge, i.e. when [piT(t-1) - piE(t-1)]² departs
significantly from zero (or a threshold k), Tunisian exports will be
heavily dependent on fluctuations in relative prices.
In order to model such phenomenon, the following formalization
may be proposed:
Suppose the transition function G (.), bound between 0 and 1,
wherein [piT(t-1) - piE(t-1)] stands for price differential, k the threshold
beyond which it is advantageous for consumers to change the
content of their consumption basket and h> 0 a parameter driving
the velocity of transition between regimes:
G([piT(t-1) - piE(t-1)] , h , k) =
It is established that when the price differential is very high
(positively or negatively) with respect to the threshold k (on the
brink as –h{[piT(t-1) - piE(t-1)]² - k} tends to infinity), function G
tends to 1, whereas when the price differential remains low (in the
sense that the distance between the price remains close to the
threshold k), function G tends to 0.
Hence, the proposed transition function makes it possible to model
a change in price elasticity based on the absolute difference in relative
prices.
Thus, the export equation can then be written as follows:
X iT(t) = a0 y(t) + a1 [piE(t) - py(t)] + f0 [piT(t) - piE(t) ] + G. f1 [piT(t) - piE(t)
]+ c + ê(t)
with: G =
Since the value of G depends on the absolute difference in relative
prices, the estimation of this equation will yield price elasticity
values between f1+f0 (to which it tends when the price differential
is high) and f0 (toward which it tends when the spread between
the prices is small).
The estimation of the model may be carried out by the non-linear
least squares method or maximum likelihood method to determine
the value of unknown parameters f0, f1, a0, a1, c, h and k.
29
6) Quantitative Rationing by Supply or Demand
It has been stated in the foregoing that the Tunisian sector export
equation:
XiT(t) = a0 y(t) + a1 [piE(t) - py(t)] + a2 [piT(t) - piE(t) ] + c
actually describes a Europe-driven demand equation. From this
perspective, it may be relevant to define such demand equation by
stating it:
(1) DmiT(t) = a0 y(t) a1 [piE(t) - py(t)] + a2 [piT(t) - piE(t)] + c
Similarly, the sector’s export supply (i) is conventionally
modelled as11 :
SXiT(t) = gS YiT(t) [PiTX(t) / PiTX(t)]sT
Where:
SXiT(t): Tunisian export volume supply of product (i)
YiT: Tunisian total production volume of product (i)
PiTD: price index of product (i) on the Tunisian domestic market (in
local currency)
PiTX: Tunisian export price index of product (i), in local currency.
gS : scale parametersT: verifying elasticity of processing sT >0
Let, in logarithms:
(2) SXiT(t) = yiT + sT [piTX(t) - piTX(t)] + c1
In the case of perfect price flexibility, the balance between supply
(7) and demand (6) will be achieved through an appropriate
adjustment of export prices12 . However, if it is assumed that there
is some export price rigidity, the quantity exported will stand at least
between supply (6) and demand (7).
An achievable estimation of a quantitative rationing model of this
type can be conducted through a CES function as follows:
(3)
wherein the supply and demand functions are defined by equations
6 and 7. Indeed, for large values of parameter ρ, the CES function
operates as operator Min.
The graph below illustrates the behaviour of the CES function with
respect to two time-varying variables S and D, where ρ = 100. It
can be observed that the CES function goes well with the minimum
of S and D.
Although the estimation of a CES function is not hitch-free, it may
be possible to econometrically estimate equation 8, in conjunction
with defining equations 6 and 7.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
11 cf. Annabi and al., 2003.12 However, it is worth noting that PiTX differs from PiT , given that it does not factor in foreign exchange conversion, or customs duties or other costs borne by European importersof commodity i.
30
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
2.2.4. Bibliography
Annabi N., Cockburn J., Decaluwé B. (2003), Formes Fonctionnelles
et Paramétrisation dans les MCEG, CREFA, Université de Laval.
De Boeff, S. (2000), Modeling Equilibrium Relationships: Error
Correction Models with Strongly Autoregressive Data, Political
Analysis, Vol 9, 14-48.
Dickey, D.A., and Fuller, W.A. (1981), Likelihood Ratio Statistics for
Autoregressive Time Series with a Unit Root, Econometrica, Vol 49,
pp 1057-72.
Engle, R.F., and Granger, C.W.J. (1987), 'Cointegration and error
correction: representation, estimation and testing, Econometrica,
Vol 55, pp 251-276.
Hurlin, C. (2001), L’Econométrie des Données de Panel, Ecole
Doctorale Edocif, Séminaire Méthodologique.
Narayan P.K. (2004), Reformulating Critical Values for the Bounds
F-statistics Approach to Cointegration: An Application to the
Tourism Demand Model for Fiji. Discussion Papers No. 02/04
Monash University.
Pesaran, M.H., Shin, Y., and Smith, R.J. (2001), Bounds testing
approaches to the analysis of level relationships. Journal of Applied
Econometrics, Vol 16, pp 289-326.
Wong, K. N. (2008), Disaggregated export demand of Malaysia:
evidence from the electronics industry. Economics Bulletin, Vol. 6,
No. 6 pp. 1-14.
2.3 Analysis of the Demand for Tunisian Goods
The purpose of the analysis is to identify "promising commodities" for
Tunisia. The methodology followed comprises two major parts. In the
first part, potentially "promising" commodities for Tunisia are identified.
The typology is based on four main criteria: level of exports (global and
vis-à-vis the European Union) by Tunisia; level of revealed comparative
advantage (RCA); and variation in exports and revealed comparative
advantage. For variations (either of exports or RCA), the reference
period is 2003-2008, so as to better identify the dynamics involved.
With respect to levels, the calculation was done by taking the mean
between 2006 and 2008, with a view to eliminating business cycle
variations. From the COMTRADE database at the most disaggregated
level (6-digit), and using the four criteria, 30 industries were identified,
representing 25% of Tunisia's exports in 2008.
While the first part focuses instead on Tunisian supply, the second
part lays emphasis on demand. Consequently, for the 30 industries,
the changes in supply for each industry were analysed.
2.3.1. Analysis of Tunisia’s Supply in terms ofcomparative advantages
The industry list provides relevant information on comparative advantages
by sector. First, at level 2, there are 7 agri-food industries (HS01 -
HS23), 3 inorganic chemical industries (HS28; phosphates), and several
W "commodities" derived from iron and steel (HS72), and electrical
machinery (85). Almost all of these industries have a positive trade
balance and for most of them, the import level is very low. They are
mainly exporting industries, with very low intra-industry trade. Regarding
the level of exports, 4 industries account fort a significant share (12%)
of Tunisian exports: 150910, 280920, 310310, and 853690.
31
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 12: Les produits potentiellement “porteurs” de la Tunisie
Product Product Name RCA Exports Trade Balance Exp. Share
030239 Tunas skipjack or stripe-bellied bonito... 0.96 58,382.56 58,381.12 0.30%
040630 Processed cheese, 0.81 29,775.37 28,811.48 0.15%
150910 Virgin 0.98 574,217.43 572,761.60 2.97%
150990 Other 0.93 46,095.95 46,053.40 0.24%
151000 Other oils..... 0.97 27,738.70 23,783.47 0.14%
151710 Margarine, excluding liquid margarine 0.87 38,352.88 38,352.31 0.20%
230690 Other 0.93 9,216.26 9,216.26 0.05%�
251010 Unground 0.94 147,511.96 147,511.96 0.76%
280920 Phosphoric acid and polyphosphoric acids 0.97 725,131.54 639,897.35 3.75%
283525 Phosphates: Calcium hydrogenorthophosphate 0.98 64,320.84 64,298.90 0.33%
283526 Phosphates:-- Other phosphates of calcium 0.97 90,545.08 90,523.38 0.47%
310310 Superphosphates 0.99 626,892.66 626,892.66 3.25%
520839 Dyed :-- Other fabrics 0.76 11,031.69 -40,415.97 0.06%
611249 Women's or girls' swimwear 0.99 35,060.86 33,570.27 0.18%
621010 Of fabrics of heading No. 56.02 or 56.03 0.97 158,879.24 146,244.53 0.82%
721030 Electrolytically plated or coated with zinc 0.52 22,776.00 19,676.60 0.12%
721049 Otherwise plated or coated with zinc 0.59 116,334.99 91,388.48 0.60%
721491 Other :-- Of rectangular cross-section 0.65 14,617.94 5,840.73 0.08%
740620 Powders of lamellar structure; flakes 0.97 20,300.78 20,244.92 0.11%
847190 Other 0.80 81,425.79 72,110.28 0.42%
851750 Other apparatus, for carrier-current line systems or for digit... 0.80 161,590.92 139,091.27 0.84%
852812 Reception apparatus for television 0.23 170,515.88 165,936.32 0.88%
853180 Other apparatus 0.93 68,192.05 63,597.62 0.35%
853690 Other apparatus 0.87 578,730.27 191,882.98 3.00%
854430 Ignition wiring sets and other wiring sets 0.70 172,225.15 -10,089.72 0.89%
854459 Other electric conductors 0.76 239,581.68 192,839.69 1.24%
854890 Other 0.87 89,169.01 69,144.95 0.46%
902830 Electricity meters 0.89 36,870.47 36,411.57 0.19%
961210 Ribbons 0.84 25,165.10 14,132.50 0.13%
961390 Parts 0.98 22,963.88 20,068.90 0.12%
Total 3,578,159.80 0.23
32
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
2.3.2. Global Demand Trends for Tunisian Expo
After identifying successful Tunisian exporting industries, the second
stage attempts to assess the demand trend and compare it with
Tunisian supply. Global demand trend for the 30 industries identified
is shown in the graph below:
Graph 5: World Imports from World 2003, 2008
The graph describes global imports for these products for two
years, 2003 and 2008, and the relative level of, and variation in,
the demand for each product. Five industries have a global
demand much higher than the rest: 721049, 852812, 853690,
854430, and 8545459. Industries for which demand has
increased the most are 251010, 230690, 310310, 854459, and
280920. For each of these five industries, global demand has
increased by more than 300%. During this period, the increase
in total global imports was a little over 110%. Twelve industries
had higher demand and two industries (030239, 851750)
experienced a decline in global demand (34% and 43%). See
also table below.
33
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Tableau 13 : World Trade with world 2003, 2008
Reporter Product Product Name 2003 2008 2008 % Variation
0 030239Tunas (of the genus Tunnus) skipjack or stripe-bellied bonito (Euthynnus (Katsuwonus) pelamis),exc lunding livers and roes : -Other
556,830.991 366,877.877 -0,341
0 040630 Processed cheese, not grated or powdred 1,310,064.957 2,383,704.616 0.820
0 150910 Virgin 2,534,737.640 4,907,778.465 0.936
0 150990 Other 788,101.796 1,256,834.297 0.595
0 151000
Other oils and theirfractions, obtained solely fromolives, wether or not refined, but not chemiccalymodified, including blends of these oils or fractionswith oils or fractions of heading N°.15.0
85,354.027 230,863.345 1.705
0 151710 Margarine, excluding liquid margarine 742,651.639 1,624,874.252 1.188
0 230690 Other 65,728.005 303,258.366 3.614
0 251010 Unground 741,393.439 3,792,910.516 4.116
0 280920 Phosphoric acid and polyphosphoric adds 1,760,366.957 7,202,665.315 3.092
0 283525Phosphates: -calcium hydrogenorthophosphate(“dicalcium phosphate”)
264,012.468 633,375.252 1.399
0 283526 Phosphate:-other phosphates of calcium 297,946.680 1,059,238.644 2.555
0 310310 Superphosphates 627,845.727 2,700,043.471 3.300
0 520839 Dyed:-other fabrics 682,166.423 742,462.914 0.088
0 611249Women’s or girls’ swimwear:-of other textilematerials
63,634.259 64,613.937 0.015
0 621010 Of fabrics of heading N°. 56.02 or 56.03 951,616.144 1,488,329.897 0.564
0 721030 Electrolytically plated or coated with zinc 3,541,817.987 7,085,701.724 1.001
0 721049 Otherwise plated or coated with zinc:-other 9,291,254.117 22,466,215.247 1.418
0 721491Other:-of rectangular (other than square) cross-section
751,400.926 2,279,521.149 2.034
0 740620 Powders of lamellar structure; flakes 112,428.911 132,925.421 0.182
0 847190 Other 4,831,012.368 6,967,781.969 0.442
0 851750Other apparatus, for carrier-current line systemsor for digital line systems
17,359,352.886 9,886,454.734 -0.430
0 852812
Reception apparatus, for teleevision, whether ornot incorporating radio-broad cast receivers orsound or video recording or reproducing appa-ratus:-colour
26,404,762.434 78,694,420.177 1.980
0 853180 Other apparatus 2,038,031.989 2,282,609.436 0.120
0 853690 Other apparatus 16,462,291.070 31,350,854.230 0.904
0 854430Ingnition wiring sets and other wiring sets of akind used in vehicules, aircraft or ships
14,839,577.745 23,516,802.519 0.585
0 854459Other electric conductors, fora voltage exceeding80v but not exceeding 1,000 v:-other
5,282,229.260 22,222,484.002 3.207
0 854890 Other 2,761,272.151 3,242,141.436 0.174
0 902830 Electricity meters 822,344.712 1,658,544.995 1.017
0 961210 Ribbons 1,345,815.367 1,706,126.056 0.268
0 961390 Parts 101,217.088 142,548.323 0.408
34
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Henceforth, the question now is to know which Tunisia’s potentially
competitive exporting countries are. To isolate the major competitors
in the 30 sectors, the ten largest exporters in the world were first
identified for 2008, and for each of the sectors, and the number of
times each country appears as the largest exporter or importer in
the selected industries was counted.
Table 14: 2008 – Number of times each country appears as key exporter or importer
Country Export Count Import Count
CHN 21 8
DEU 18 21
FRA 16 23
TUN 15 2
USA 15 21
ITA 13 16
ESP 12 18
NLD 12 14
BEL 11 12
GBR 10 20
JPN 10
MEX 9 8
TUR 9 1
ISR 6 1
KOR 6 5
CZE 5 1
MAR 5 1
POL 5 7
TWN 5 3
After identifying the "competitor" countries, it is interesting to assess
the level of similarity in the structure of exports between these countries
and Tunisia. The revealing indicator is Finger-Kreinin (FK). It allows a
comparison between the export structures of two countries. If the
structures are identical, FK is equal to "1", in case both countries have
totally different structures, which means there is no commodity exported
by both countries, FK is equal to "0". Table 3.15 provides the FK
between Tunisia and all countries identified in the table above. It
appears the level of similarity is highest with Morocco and Mexico
(0346 and 0334), followed by Turkey, and then some European
countries. The level of similarity is lowest with Israel, Japan, Korea,
and Taiwan. An indicator value of 0346 can be interpreted as a degree
of similarity of export structures of approximately 34.6%. In comparison,
the level of similarity between the U.S. and the EU is about 65%.
35
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 15: FK Index for Tunisia and a Group of Competitor Countries
Country 2003 2004 2005 2006 2007 2008
BEL 0.160 0.137 0.157 0.173 0.177 0.185
CHI 0.205 0.187 0.199 0.206 0.211 0.210
CZE 0.153 0.154 0.178 0.176 0.184 0.191
FRA 0.165 0.161 0.183 0.194 0.203 0.204
DEU 0.152 0.147 0.167 0.177 0.180 0.181
ISR 0.080 0.078 0.081 0.087 0.099 0.110
ITA 0.205 0.199 0.222 0.232 0.232 0.236
JPN 0.092 0.092 0.105 0.117 0.125 0.132
KOR 0.126 0.104 0.117 0.131 0.134 0.141
MEX 0.245 0.261 0.320 0.293 0.333 0.334
MAR 0.380 0.384 0.376 0.353 0.342 0.346
NLD 0.164 0.141 0.157 0.166 0.167 0.182
POL 0.174 0.166 0.192 0.198 0.200 0.202
ESP 0.192 0.188 0.206 0.214 0.217 0.231
TUR 0.268 0.250 0.267 0.270 0.267 0.265
GBR 0.207 0.194 0.212 0.225 0.238 0.251
USA 0.144 0.140 0.155 0.171 0.167 0.179
TWN 0.122 0.113 0.125 0.145 0.143 0.149
In dynamics, the level of similarity with all countries (except Morocco
and Turkey) increased. FK with Morocco declined slightly over this
period, indicating a differentiation in specialization by both countries.
The increase in the index is most significant with Japan, Mexico,
and Israel. Hence, as regards the exports structure, it seems the
biggest competitors globally are some European countries (Czech
Republic, France, Italy, Spain), and Morocco but less so at the end
of period.
Unlike the FK index, the RECPI index takes into account the level
of exports. The table below gives the RECPI for Tunisia and the 18
countries, while considering their global exports. The higher the
number, the stronger the competitive pressure.
The key competitor countries are Mexico, United Kingdom, United
States, China and Nederland. The country whose competitive
pressure on Tunisia has increased the most is Korea.
36
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 16: Indice RECPI de la Tunisie etd’un groupe de pays concurrents
Country 2003 2004 2005 2006 2007 2008
BEL 3.36 1.99 2.48 3.18 2.19 2.55
CHI 4.95 3.65 4.82 5.62 4.08 3.99
CZE 0.33 0.27 0.37 0.39 0.30 0.35
FRA 2.52 1.56 2.04 2.55 1.56 1.72
DEU 4.04 3.10 3.82 4.52 2.95 2.80
ISR 0.12 0.07 0.06 0.07 0.06 0.12
ITA 3.39 2.31 2.77 3.32 2.33 2.22
JPN 1.44 1.21 1.49 1.81 1.36 1.68
KOR 2.08 1.30 2.08 2.86 1.93 2.59
MEX 9.07 9.30 13.44 14.73 13.01 11.04
MAR 0.48 0.39 0.63 0.33 0.22 0.41
NLD 4.02 2.10 3.02 4.20 2.87 3.72
POL 0.47 0.35 0.46 0.55 0.40 0.44
ESP 1.75 1.48 1.52 1.95 1.20 1.37
TUR 1.16 0.88 0.90 0.97 0.72 0.75
GBR 8.83 7.79 10.26 11.31 9.52 8.71
USA 3.94 2.45 3.27 4.64 3.01 4.78
TWN 1.24 0.87 1.28 1.70 1.12 1.23
The table below reviews the level of similarity for the five largest
Tunisian exports sectors at 2-digit HS level. They account for over
60% of exports. For each of these sectors, the comparison
involves the level of similarity between Tunisia and the 18 countries
identified as key competitors. In the table, for each sector, the
five countries with the highest level of similarity are shown in red,
and the most significant in "bold". There are noticeable differences
among the sectors regarding the most significant competitors.
Morocco is one of the five most significant competitors in 4
sectors. Three countries, namely: Turkey, Belgium, and China are
in 3 areas. However, the variance is quite high across sectors. If
electrical appliances are taken into consideration, many countries
will have fairly identical levels of similarity. However, as regards
the inorganic chemicals sector, Morocco stands out as probably
the most significant competitor. Consequently, it is important to
consider the policies in these countries and the development of
their trade in key sectors when formulating subsequent relevant
policies.
37
2.4 Impacts of Opening up Tunisia’s Economyon the Production System and Analysis of theBusiness Adaptation Process
Productivity growth achieved by an economy as a whole may ensue
from two main sources:
- The internal dynamics of (or peculiar to) businesses; and
- The reallocation processes, among which the following
distinctions must be made:
- Reallocation among businesses within the same sector (usually
from the least efficient to the most efficient). This is intra-sector
reallocation;
- Reallocation of businesses across sectors (inter-sector
reallocation); and
- Reallocation through the entry and exit of firms (if in-coming
businesses are more efficient than out-going ones, then the net
impact on the production system is positive).
The objective of this part of the study is to assess the contribution
of these mechanisms to the dynamics of the Tunisian economy.
From a methodological standpoint, it was agreed that the productivity
decomposition method be applied. This method specifically identifies
the extent to which productivity growths are attributable to increased
productivity within businesses or to the phenomenon of reallocation.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 17: Tunisia’s Competitors by Sector
Mineral Fuels Electrical Machinery Apparel & Clothing FertilisersInorganicChemicals
27 85 62 31 28
CZE 0.217 0.350 0.587 0.005 0.105
TRU 0.212 0.322 0.521 0.517 0.143
GBR 0.712 0.247 0.444 0.155 0.023
USA 0.244 0.231 0.468 0.575 0.070
BEL 0.254 0.265 0.513 0.077 0.172
CHI 0.306 0.237 0.461 0.307 0.134
FRA 0.214 0.342 0.434 0.032 0.016
DEU 0.214 0.284 0.504 0.010 0.024
ISR 0.217 0.139 0.283 0.219 0.300
ITA 0.246 0.316 0.442 0.078 0.033
JPN 0.214 0.216 0.426 0.006 0.023
KOR 0.213 0.167 0.259 0.226 0.038
MEX 0.911 0.298 0.501 0.750 0.183
MAR 0.212 0.360 0.509 0.742 0.660
NLD 0.218 0.221 0.540 0.041 0.060
POL 0.215 0.358 0.508 0.025 0.112
ESP 0.214 0.330 0.446 0.092 0.117
TWN 0.213 0.145 0.294 0.001 0.030
38
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
2.4.1. Descriptive Analysis of Tunisia’s IndustrialBusiness Database
All data in the database are derived from annual surveys conducted
by the National Institute of Statistics of Tunisia and made available
to ITCEQ. The database contains data on Tunisian industrial
sectors from 1997 to 2007. It has information on production,
intermediate consumption, permanent employment, seasonal
employment, activity sectors, the region and capital structure. The
transition to constant prices was done by using the production
price indices, value-added price indices and 5-digit intermediate
consumption price indices provided by the INS. The business
performance indicator used is labour productivity, determined for
each company by calculating the ratio of value added at constant
prices to the entire workforce, which comprises both the
permanent and seasonal workers.
By retaining only the industrial sector, the "raw" initial database has
16,442 remarks, representing 4,464 businesses. Once cleaned
(detailed cleaning procedure in Box 1), the unbalanced panel
database includes 15 202 remarks and 4206 businesses.
Table 3.18 shows the breakdown of sample firms by sector. The
most prominently represented are apparel (29%) and agri-food
industries (13%). They alone account for 42% of firms in the sample.
The automotive sector, however, only accounts for 2% of the number
of firms, followed by the chemicals & pharmaceuticals, rubber &
plastics sectors (4% each).
Table 18: Number of Businesses by Sector
Sector Number of Businesses In percentage
1 Agri-food and Tobacco 561 13%
2 Textile 262 6%
3 Apparel 1236 29%
4 Footwear and Leather 250 6%
5 Timber, Paper and Publishing 283 7%
6 Chemistry and Pharmaceuticals 179 4%
7 Rubber and Plastics 159 4%
8 Non-metal Material 314 7%
9 Metal Materials 320 8%
10 Electrical Machinery, Machines and Appliances 329 8%
11 Automotive Industry and other Transportation Equipment 102 2%
12 Furniture 211 5%
The breakdown of 4,206 businesses by size was conducted based
on the criterion of average total employment of each business by
using the quantiles method. The resultant breakdown classifies
companies with a total number of employees not exceeding 23 under
the "small" group. In other words, the first third of the sample firms
have, on average, a number of employees not exceeding 23. In the
"medium" group (which corresponds to the second third of
businesses), businesses have a number of employees strictly greater
than 23 and not exceeding 77. "Large" group (the last third of sample)
firms have more than 77 employees.
39
Table 3.19 shows the breakdown of businesses by size and by
the number of years of presence in the database. The first row
of the table shows, for instance, that among the 1,469 firms
present in a single year, half of them (i.e. 732) fall under the
"small" category, about a third (or 455) belong to the " medium"
category and 19% (i.e. 282 companies) are considered "large".
Therefore, arrival and disappearance from the sample (which, it
should be recalled, are not necessarily new businesses or
cessation of activities) concern more of small firms. The
distribution by size of companies present for five years generally
corresponds to breakdown by quantile of 4206 businesses in
the sample. Approximately 80% of companies in the database
for 11 or 10 years fall under the "large" business category. On
average, companies with over 77 employees are present in the
sample during a number of years higher than the "medium" and
especially "small" categories.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 19: Number of Businesses by Size According to the Number of Years of Presence in the Database
Number of years ofpresence in the database
Number Percentage
Total Small Medium Large Small Medium Large
1 1469 732 455 282 50% 31% 19%
2 561 195 205 161 35% 37% 29%
3 469 144 172 153 31% 37% 33%
4 327 84 104 139 26% 32% 43%
5 322 114 106 102 35% 33% 32%
6 318 68 109 141 21% 34% 44%
7 205 27 78 100 13% 38% 49%
8 178 17 67 94 10% 38% 53%
9 140 10 46 84 7% 33% 60%
10 128 3 24 101 2% 19% 79%
11 89 1 15 73 1% 17% 82%
Table 3.20 dwells on the breakdown by size of businesses in the
database within the various sectors. For example, the second part
of the table shows that the breakdown in sector 10 (Electrical
Machinery) is closest to the distribution of firms across the database.
30% of companies are indeed small-sized, 36% are medium-sized
and 35% are large. However, the figures in bold or underscored in
gray highlight where the percentages substantially differ from those
that correspond to all the sectors. The highest fall in bold and the
lowest percentages are highlighted in gray. It is found that companies
in the "small" category are relatively more present in the timber, paper
& publishing sector (58%), Agri-food industries (57%), furniture
manufacturing (51%) and metal materials (45%) sectors. However,
they are less present in two sectors: apparel (10%) and footwear
and leather (23%). It is in this leather and footwear sector alone that
“medium-sized” companies are relatively the most active, with a 40%
share. Furthermore, it is only in one sector (Agri-food industries) that
these "medium-sized" businesses are relatively less prevalent (21%).
Lastly, companies considered "large" are more strongly represented
in apparel (57%), but relatively less present in timber, paper &
publishing (13%), metal materials (17%) agri-food industries (22%).
40
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
The table below shows the breakdown of firms by capital structure
and by size. Among the 4,206 businesses in the sample, 126 (3%)
have part of their capital held by the State and 1,243 (30%) have
part of their capital held by foreign investors. The firms concerned
fall mainly under the "large" category (58% for capital held by the
State and 65% for capital held by a foreign entity).
Table 3.22 shows the number of businesses by major region. It is
found that the vast majority of businesses in the sample are located
in the district of Tunis, the North East and Central East. Only 6%
of the 4,206 firms are located in the North West, 3% are located
in the South (East and West) and 2% of the sample in the Centre
West.
Table 20: Breakdown of Businesses by Sector and by Size
Number of years of presence in the database
Number Percentage
Total Small Medium Large Small Medium Large
1. Agri-food and Tobacco 561 317 119 125 57% 21% 22%
2. Textile 262 96 103 63 37% 39% 24%
3. Apparel 1236 124 406 706 10% 33% 57%
4. Footwear and Leather 250 57 101 92 23% 40% 37%
5. Timber, Paper & Publishing 283 163 82 38 58% 29% 13%
6. Chem. and Pharmaceuticals 179 68 62 49 38% 35% 27%
7. Rubber and Plastics 159 61 62 36 38% 39% 23%
8. Non-metal Materials 413 124 109 81 39% 35% 26%
9. Metal Materials 320 145 121 54 45% 38% 17%
10. Electrical Machinery 329 98 117 114 30% 36% 35%
11. Automotive Industry 102 35 28 39 34% 27% 38%
12. Furniture 211 107 71 33 51% 34% 16%
Table 21: Breakdown of Businesses by Sector and by Size
Number of years of presence in the database
Number Percentage
Total Small Medium Large Small Medium Large
Businesses that have at least part of their capital held by the State
126(i.e. 3% of 4206businesses)
24 29 73 19% 23% 58%
Businesses that have at least part of their capital held by foreign private investors
1243(i.e. 30% of 4206businesses)
107 334 802 9% 27% 65%
41
Table 23 shows unweighted average productivity by corporate
capital structure. It is found that businesses whose capital is held
in whole or in part by the State or foreign investors have, throughout
the period, an average productivity higher than all businesses.
However, no causal link may be inferred, given especially that, as
shown above, these firms fall mainly under the "large" category of
businesses. It is therefore not surprising to observe a higher average
productivity for both categories of businesses.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 22: Number of Businesses by Major Region
Regions Number of Businesses In percentage
1. District of Tunis and North East 1829 45%
2. North West 246 6%
3. Centre East 1731 43%
4. Centre West 95 2%
5. South East and West 122 3%
Total 4023* 100%
Corporate Capital Structure Unweighted Average Labour Productivity
Businesses that have at least part of their capital held by the State 9.22
Businesses that have at least part of their capital held by foreign private investors
8.71
* 183 businesses did not provide information on their location. Hence, the figures available fall short of the total number of businesses in the database, which stands at 4206.* This is the unweighted average, on all 11 years, expressed in log.
Table 24 provides the weighted average productivity per year
(expressed in log), which is also shown graphically (Graph 6). During
the past 11 years, the labour productivity of Tunisian businesses
in our sample rose sharply. Labour productivity (weighted average)
increased from 9.42 in 1997 to 9.67 in 2006 (which is a 25%
increase) and 9.91 in 2007 (i.e. 49% increase, still with respect to
1997). With respect to annual growth rates, productivity declined
only between 2002 and 2003 (5%), between 2003 and 2004 (1%)
and between 2004 and 2005 (1%). The strong productivity growth
registered between 2006 and 2007 (+24%) is quite surprising and
should be considered with caution. Indeed, the year 2007 is
characterized by a significant turnover of businesses in the sample.
Table 23: Average Labour Productivity by Capital Structure
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T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
As shown in Table 24, 30% of firms in 2007 were never previously
present in the database. It seems that these arrival and
disappearance of businesses have greatly contributed to such
increase in productivity between 2006 and 2007. Although INS
uses a number of procedures to ensure the representativeness of
the samples surveyed, caution must be exercised in interpreting
results when working on databases which are not from censuses.
Furthermore, to avoid distorting the interpretations, some graphs
will be presented: (i) covering the entire period (i.e. from 1997 to
2007) and (ii) leaving out the last year (i.e. from 1997 to 2006).
Graphs 3.4a show the weighted average labour productivity by
sector, first between 1997 and 2007, and then between 1997 and
2006.
If 2007 is disregarded, it will be discovered that labour productivity
fell in five sectors: textiles (sector 2), apparel (sector 3), chemicals
and pharmaceuticals (sector 6), rubber and plastics (sector 7) and
automotive (sector 11).
For the first 3 sectors (textiles (2) , apparel (3) and chemicals and
pharmaceuticals (6), the strong productivity growth registered
between 2006 and 2007 helps to avoid the foregoing cuts and to
end up in 2007 with productivity levels higher than in the beginning
of the period (i.e. 1997). In Sector 7 (rubber and plastics), labour
productivity also increased sharply between 2006 and 2007, but
not enough to exceed the productivity level of 1997. In addition, a
glance at the graphs over the period 1997-2007 reveals that only
YearWeighted average productivity (in log)
Annual growth rate of weightedaverage productivity
Productivity growth rate withrespect to 97
1997 9.42
1998 9.45 3% 3%
1999 9.49 4% 7%
2000 9.58 9% 16%
2001 9.61 3% 19%
2002 9.66 5% 24%
2003 9.61 -5% 19%
2004 9.60 -1% 18%
2005 9.59 -1% 17%
2006 9.67 8% 25%
2007 9.91 24% 49%
Table 24: Labour Productivity Trend for all Businesses in the Sample
43
one sector, the automotive sector (sector 11), experienced a
significant drop in its labour productivity.
In contrast, Labour productivity increased in seven sectors: food and
agricultural (sector 1), leather and footwear (sector 4), timber, paper and
publishing (sector 5), non-metal materials (sector 8), metal materials
(sector 9), electrical machinery (sector 10) and furniture (sector 12).
Among these sectors, labour productivity growth is particularly marked
in the food and agriculture sector (1), timber, paper and publishing (5),
non-metal materials (8), metal materials (9) and electrical machinery (10).
Graph 3.4b shows the labour productivity trend by corporate capital
structure between 1997 and 2007 and depicts, in solid line, the
category of businesses whose capital is wholly held by the State,
and in dotted line, the category of firms with at least part of their
capital held by foreign investors.
It is clear that the productivity of domestic firms rose more sharply
than that of companies with foreign capital. In 1997, the
productivity of domestic businesses stood at 9.32. It increased
to 9.72 in 2006 and to almost 10 in 2007. For companies with
foreign capital, it increased from 9.58 in 1997 to 9.68 in 2006
and 9.82 in 2007.
Between 1997 and 2003, the productivity of companies having
foreign capital is higher than that of domestic firms. From 2003,
the reverse is true: labour productivity of domestic firms becomes
higher than that of firms with foreign capital.
This mind-boggling outcome is interesting, and requires a more
detailed specific analysis. Indeed, it is generally expected that
businesses owned in part by foreign investors will experience more
substantial productivity growth.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
44
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Graphs 6: Weighted Average of Labour Productivity Trend by Sector between 1997 and 2007 (in log)Between 1997 and 2006 (in log)
Between 1997 and 2006 (en log)
45
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Graphs 7: Weighted Average of Labour Productivity Trend by Size between 1997 and 2007 (in log)Between 1997 and 2006 (in log)
Between 1997 and 2006 (en log)
Graph 8: Weighted Average of Labour Productivity Trend by Corporate Capital Structure (in log)
46
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
2.4.2. Productivity Decomposition Analysis
2.4.2.1. Definitions and Methodology
Labour productivity growth in businessesmay be related to either:
- unanticipated cyclical changes in demand by businesses, which
generally account for frequent "unintentional" slumps in labour
productivity;
- labour market rigidities that can slow down the adaptation of the
number of employees (upward or downward) to changes in
production; or
- a set of firm-specific decisions that can lead to improved
productivity. These include, for example, improving the standard
of employee training, investing in the procurement of more efficient
machines, use of better quality inputs, corporate reorganization,
redundancy-related decisions, etc.
The phenomena of reallocation may ensue from inter-sector
changes (some sectors develop while others stagnate or decline),
or intra-sector changes, i.e. market share variations as well as
corporate arrivals and disappearances occur within each sector.
For a long while, because only sector data (from either domestic
or international sources provided by UNIDO) were available, the
reallocation analysis focused on inter-sector changes, given that
the homogeneous firm assumption posited by both traditional
international trade theories and the New Trade theory (Krugman,
1979, Helpman and Krugman, 1987) does not help to explain,
theoretically, the possibility of intra-industry reallocation. The recent
development of the "New New Trade" theory, initiated in particular
by Melitz (2003), and characterized by consideration of the
heterogeneity of businesses within sectors, justified theoretically,
that the analysis should focus on changes within firms. Access to
the individual databases of companies helped to develop empirical
analyses in furtherance of these theoretical advances. Hence, the
main lessons learned from recent theoretical and empirical
developments in the literature are only within the same industry.
There are companies that can be very outstanding, owing to their
size, degree of integration into the international economy, level of
productivity, etc. and that, in this context, any change (trade reform,
business environment, change in international demand, increased
competition, etc..), will impact differentially on these businesses
and necessarily engender reallocations within sectors. The
predominant concept from the literature is that these intra-industry
reallocations would be of much greater magnitude than those
occurring between sectors. In this theoretical framework, Melitz
(2003, cited above) has shown, for instance, that opening up to
international trade leads to increased market shares for businesses
that were initially the most productive to the detriment of the less
productive ones, which disappear or see their market share
dwindle. For these authors of "New New Trade", changes in the
aggregate productivity of an economy are due mainly to the
reallocation of such phenomena within industries, especially when
it comes to savings open to international trade.
In the literature, the 3 main methods used are those of Foster,
Haltiwanger Krizan (FHK, 1998 and 2001), Griliches and Regev
(GR, 1995) and, more recently, Pavcnik (2002). Although the FHK
method is the most comprehensive, it requires, as does also the
GR method, knowledge of the arrival and disappearance of
businesses. Given that data on Tunisian firms do not allow for the
identification of "real" arrivals and disappearances, the only method
applicable in this case is Pavcnik's.
This decomposition method was applied (i) across the entire sample,
(ii) by sector, (iii) by size and (iv) by corporate capital structure. In all
cases, the results are shown in terms of change from the start year,
i.e. 1997. In the four tables below, the second column indicates
changes in aggregate productivity with respect to 1997. The following
two columns correspond to variations of the first and second term
in the decomposition. As required by the decomposition equation,
the sum, online, of columns (3) and (4) corresponds to column (2).
2.4.2.2. Findings of Business Survey Processing
Table 25 shows the outcome of the entire sample. Column (2), which
indicates changes in aggregate labour productivity for all businesses,
is the last column of Table 12 already presented above. It is found
47
that much of the productivity growth is derived from the reallocation
effect. In 2006, the 25% aggregate labour productivity growth rate
were due to the 8% from productivity growth within businesses,
17% from the reallocation of resources from less efficient to the
most efficient firms. In other words, 67% of the variation in aggregate
productivity over 10 years (97-2006) is due to the increase in the
covariance term. In 2007, the same share stood at 72%. Although
this covariance term did not increase regularly throughout the period,
it is always positive (except only for the first two years), which shows
that reallocation plays in the right direction, i.e. the most productive
firms are developing and/or the least productive ones have decreasing
market shares.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
(1) Year(2) Aggregate Productivity Growthtedaverage productivity (in log)
(3) Variation in unweighted Productivity(First term)
(4)Variation in Covariance (Second term)
1997 0.000 0.000 0.000
1998 0.023 0.055 -0.031
1999 0.071 0.072 -0.001
2000 0.153 -0.038 0.191
2001 0.183 0.043 0.140
2002 0.235 0.124 0.112
2003 0.183 -0.126 0.057
2004 0.172 -0.109 0.062%
2005 0.164 -0.079 0.085
2006 0.249 0.081 0.168
2007 0.486 0.138 0.348
Table 25: Decomposition of Aggregate Productivity Growth for the Entire Sample
While it is true that, for the entire sample, reallocation contributed
significantly to aggregate productivity growth, it is worth
underscoring also that such assertion still needs to be verified in
the sectors. In fact, it is only in two industries (footwear and
leather and metal materials), that changes in the covariance term
are always positive throughout the period and higher than corporate
productivity. However, in six sectors, (textiles, chemicals and
pharmaceuticals, rubber and plastics, non-metal materials, electrical
machinery and furniture), corporate productivity increased, while the
covariance term had a negative impact on the variation of aggregate
productivity. In the timber, paper and publishing sectors, the dominant
effect is labour productivity growth within businesses. In the food
and agricultural sector, productivity growth is also due, throughout
the period, to the productivity growth of businesses, except for the
last 2 years (2006 and 2007) during which contributions from the
covariance term were particularly significant. Lastly, in two sectors,
the apparel and automotive sectors, these two terms (corporate
productivity and covariance), played a negative role on the change
in aggregate labour productivity.
The impact of reallocation contributed significantly to the aggregate
labour productivity growth for the "average" and "large" categories
of businesses. With the exception of 1998, the variation of the
covariance term was indeed always positive for these two groups of
48
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
businesses. For the "small" category, that term varied positively only
for four years (2000, 2001, 2005 and 2007). The strong growth of
the covariance term in 2007 should be considered with caution, given,
as already underscored above, the crucial survey sample rotation
particularly relevant to "small" businesses. These results also show
that "medium"-sized businesses, for the most part, increased their
unweighted labour productivity. It would be interesting to understand
the factors that prompted them to improve their efficiency and the
means by which they achieved it.
The results of the decomposition of aggregate labour productivity
by corporate capital structure shows, in the sample, that the
reallocation effect tended to contribute to aggregate productivity
growth only for businesses that are entirely domestic. For firms
with part of their capital held by foreign investors, the variation in
the covariance term is positive only for 4 years (2000, 2001, 2002
and 2007). With regard specifically to entirely domestic businesses,
the 40% increase in aggregate labour productivity in 2006 can be
broken down as follows: 7% accounts for labour productivity
growth within businesses and 33% is derived from the reallocation
effect. In 2007, the 68% increase in aggregate productivity ensued
from productivity growth within businesses (14%) and the
reallocation effect (54%).
2.4.2.3. Conclusion
Under the project, labour productivity of Tunisian businesses in the
industrial sector was analysed between 1997 and 2007, from a
sample of individual firms from annual surveys. The key findings of
this analysis are as follows:
First, the aggregate labour productivity of Tunisian businesses rose
sharply. It increased by 25% between 1997 and 2006 (and by 49%
between 1997 and 2007, although the past year should be
considered with extreme caution, given that 30% of the sample
was renewed);
Second, at the sector level, aggregate labour productivity
increased in seven industries (Agri-food, leather and footwear,
timber, paper and publishing, non-metal materials, metal materials,
electrical machinery and furniture). However, if year 2007 is
disregarded, aggregate productivity fell in five sectors (textiles,
apparel, chemicals and pharmaceuticals, rubber, plastics and
automotive);
Third, while unweighted average productivity throughout the
period is higher for "large" firms than for "average" ones, aggregate
productivity grew faster for "medium"-sized businesses than for
"large" firms. From 2003 to 2006, the aggregate labour productivity
of "average" businesses exceeds that of "large ones;
Fourth, the aggregate labour productivity of domestic firms rose
more sharply than that of companies with at least part of their
capital held by foreign investors; and
Lastly, the decomposition results highlighted the role of resource
reallocation from less efficient to more efficient businesses in
boosting aggregate labour productivity across the entire sample.
The 25% productivity growth rate between 1997 and 2006 is
accounted for by 8% in labour productivity growth within
businesses and 17% from the reallocation effect. This is true
especially for domestic firms and "medium-" and "large-"sized
firms. However, at the sector level, this result is only true for 2
industries (footwear and leather, metal materials). Labour
productivity growth within businesses involved a larger number of
sectors (Agri-food, textiles, timber, paper and publishing, chemicals
and pharmaceuticals, rubber and plastics, non-metal materials,
electrical machinery and furniture).
49
Disney, R., J. Haskel and Y. Heden (2003), Restructuring and
productivity growth in UK manufacturing, Economic Journal,
Vol. 113, No. 489, pp. 666 – 694.
Foster, L., J.C. Haltiwanger and C.J. Krizan (1998), Aggregate
productivity growth: Lessons from microeconomic evidence, Working
Paper 6803 NBER.
Foster, L., J.C. Haltiwanger and C.J. Krizan (2001), Aggregate
productivity growth: Lessons from microeconomic evidence, in Edward
Dean, Michael Harper, and Charles Hulten (eds.), New Developments
in Productivity Analysis, Chicago: University of Chicago Press.
Griliches, Z. and H. Regev (1995), Firm productivity in Israeli industry
1979-1988, Journal of Econometrics, 65, pp. 175-203.
Hall, B. H. and J. Mairesse (1995), Exploring the relationship between
R&D and productivity in French manufacturing firms, Journal of
Econometrics, Elsevier, 65(1), pp. 263-293.
Helpman E. and P.R. Krugman (1987), Market Structure and
Foreign Trade: Increasing Returns, Imperfect Competition, and the
International Economy, MIT Press Books, The MIT Press.
Krugman, P. R. (1979), Increasing returns, monopolistic competition,
and international trade, Journal of International Economics, 9(4),
pp. 469-479.
Melitz, M. (2003), The Impact of Trade on Intra-Industry Reallocations
and Aggregate Industry Productivity, Econometrica, 71, pp. 1695–1725.
Pavcnik, N. (2002), Trade Liberalization, Exit, and Productivity
Improvements: Evidence From Chilean Plants, Review of Economic
Studies, 69, pp.245-276.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Bibliography
50
3. Training
The training of ITCEQ executives was an essential component
of the project. Two training sessions, the first in November 2010,
and the second in April and May 2011, allowed ITCEQ and DEFI
experts to develop constructive cooperation ties. These training
sessions in Aix-en-Provence and Tunis fostered the transfer of
knowledge in quantitative methods and discussed matters of interest
to ITCEQ. ITCEQ experts have course materials, STATA programmes
and access to DEFI databases. The non-exhaustive training reports
presented below outline the themes and methods addressed.
3.1 Example of Econometrics Training Sessionand Macroeconomic Modeling
29 November: Estimations using the Eviews software
Morning and Afternoon:
DEFI experts: Marcel Aloy, Eric Heyer
This day was devoted to the application of econometric techniques
on time series data presented the previous days.
Plan for the day
1. Recap of the main econometric tests on time series data
2. Introduction to the Eviews software
3. Estimations of various behavioural equations on French data
a. ECM in 2 stages
b. ECM in 1 stage
Tuesday 30 November: Presentation of various domestic models
Morning and Afternoon:
DEFI experts: Marcel Aloy, Eric Heyer
Throughout this day, the structure and properties of the domestic
models existing in France were reviewed by comparing, most
particularly, the OFCE model (emod.fr) to that of the Ministry of the
Economy (Mésange).
Plan for the day
1. Accounting framework
2. Pattern of causalities
3. Transparency of causalities
4. Model size
5. Key behaviours
a. Consumption
b. Investment
c. Employment
d. Wage-price setting
e. External trade
6. Multiplier
a. Mechanism
b. Decomposition by major aggregate
c. Multiplier over time
d. Why does it vary?
e. Multiplier during the crisis.
7. Modeling Instruments
a. Error correction model
b. Conventional writing
c. The long run and cointegration
d. Dynamics
Wednesday 1 December: Structural properties of modelling &
estimations on Tunisian data
Morning:
DEFI experts: Marcel Aloy, Eric Heyer
Throughout this morning, the structural properties of modelling were
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
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T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
reviewed with special emphasis on the notions of potential growth
and structural unemployment.
Plan for the morning
1. Potential production
a. Structural assessment
b. Filter assessment
2. Structural unemployment
a. Structural assessment
b. Filter assessment
3. Review of various assessments and their impacts on economic
policy
Afternoon:
DEFI experts: Marcel Aloy, Eric Heyer
During this afternoon, Tunisian data were used to estimate the
employment- and price-value added equations for the various sectors.
3.2 Example of Training on Business DataProcessing
Tuesday, 23 November
Morning and Afternoon:
DEFI expert: Gilbert Cette
Presentation of the analyses of potential production and methods
of calculating labour productivity: (see Slides of working sessions in
Appendix).
Wednesday, 24 November
Morning and Afternoon:
DEFI expert: Marion Dovis
1. Presentation of methods for cleaning databases (see slides in
Appendix),
2. Presentation and explanation of major commands for the
management of databases on Stata (see slides in Appendix),
3. Work on Survey Data: Contrary to expectations, ITCEQ does
not have a comprehensive database bringing together all available
variables from the Survey data. In fact, data exists, solely on
Excel files separated by year and type of variables. However,
clean-up has to be performed on a single database. This
observation warranted that the creation of a complete index
of variables be added to the initially planned programme13.
4. Establishment of a single database containing all the available data
from surveys: These data are on Excel files separated by year and
by category of variables (results status, employment, liabilities,
assets, capital assets, identification, accounting values and other
book values and suite). The transition from these Excel files to a
full database on Stata would require the:
- harmonization of all Excel files to make them comparable;
- establishment of correspondences between different questionnaires
(questionnaire change from 98);
- addition of price indices; and
- merger of all these files so as to have a complete STATA package.
This study would normally require at least 3 or 4 working days. To carry
13 The initially scheduled work programme required that these data should be ready on a STATA database.
52
out the scheduled Training component within the same timeframe
and, in general, meet the set objectives of this mission, this work
was done largely at night and during the weekend by DEFI experts
(mainly M. Dovis). To avoid loss of time, Mr. Dovis provided ITCEQ
executives with an initial version of the database on Stata on Friday
afternoon, (so they can do the preparatory work of cleaning, and
get trained on Stata for the application of the session on the key
commands used, etc.).
Thursday 25 November
Morning:
DEFI expert: Patricia Augier
Presentation and explanation of the various productivity
decomposition measures used in scientific literature.
ffAfternoon:
DEFI experts: Patricia Augier, Marion Dovis
Harmonization of the various initial databases:
(i) Discussion on the correspondence between the 1997questionnaire
and the one used from 1998.
(i) Preparation of the programming file for the merger of various
databases.
Friday, 26 November
Morning and afternoon:
DEFI expert: Marion Dovis
1. Continuation of the preparation of the programming file for the
merger of various databases.
2. Preparation of a preliminary version of the database for ITCEQ
executives so that they could start the initial descriptive analyses
in preparation for cleaning programmes.
3. Labelling the variables available in the database.
Thursday, 29 November
Morning:
DEFI expert: Marion Dovis
Finalization and verification of the merger of databases with all the
variables.
Afternoon:
DEFI experts: Patricia Augier, Marion Dovis
1. Verification of correspondences between the 1997 survey
questionnaire and the one used from 1998, particularly for the
profit and loss account and for employment. A file specifying
the transition between both questionnaires was prepared. For
cases not brought up for discussion, the calculation of
correlation coefficients was verified. The findings of these
correlation tests are specified on the relevant transition file (see
Appendix).
2. Preparation of a clean-up programme.
Tuesday, 30 November
Morning and Afternoon:
DEFI experts: Patricia Augier, Marion Dovis
1. Preparation of the clean-up programme.
2. Analysis of Inventory data to assess the possibilities of its use.
3. Discussion on the choice of the most appropriate productivity
decomposition method. It was agreed that an intuitive method
be chosen based on what is intended to be highlighted.
Furthermore, the issue of not identifying in-coming and out-going
businesses on the market should be considered when choosing
the decomposition method.
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Wednesday, 1 December
Morning and Afternoon:
DEFI experts: Patricia Augier, Marion Dovis
1. Verification of the clean-up programme and detailed Explanation
of the various stages.
2. Discussion on possible changes to be introduced from the
baseline programme proposed and implemented by DEFI
experts.
3. Discussion on decomposition methodologies.
Thursday, 2 November
Morning and Afternoon:
DEFI experts: Patricia Augier, Marion Dovis
1. Discussion on decomposition methodologies.
(i) Choice of the method to be used
(ii) Choice of software to be used for programming.
2. Analysis of mission accomplishments with respect to expected
objectives and programming of the latter part of the project (see
details of these points in the following paragraph).
54
4. Conclusions
i) The ITCEQ/DEFI Technical Assistance Programme, whose
initially planned duration was 4 months, has actually been
implemented over 8 months, mainly because of the events
of January 2011 in Tunisia. The scope of the project was
very wide and some aspects have only been partially
addressed. However, in these few cases, the theoretical and
methodological elements were covered, thereby paving the
way for subsequent empirical validations.
ii) The training component met the set objectives mutually
agreed upon with ITCEQ experts during the start-up mission.
• ITCEQ experts were trained in econometrics and macro-
economic modelling. With respect to Quantitative techniques,
several sessions were devoted to processing software, especially
Stata, given that ITCEQ experts were more familiar with Eviews.
• ITCEQ experts were trained in theoretical macroeconomic
modelling. On this occasion, they were informed on
macroeconomic models used in major European forecasting
institutions.
• Lastly, ITCEQ experts were trained in components 2.2 and 3.
- ITCEQ executives were trained on methods of cleaning micro-
economic data used in the literature;
- TITCEQ executives received training on the management of
databases on Stata;
- ITCEQ executives have a merged and therefore complete
database, with all the variables;
- ITCEQ executives have the clean-up programme on Stata, and
the cleaned database with all the variables ready for immediate
use and/or which can be modified. This programme was
designed in such a manner as to enable ITCEQ executives to
subsequently modify it to their liking;
- ITCEQ executives were trained on the decomposition methods
used in the literature;
- The implementation of decomposition methods may be carried
out using various software such as Excel, Stata or Gauss. DEFI
experts and ITCEQ executives agreed that it was appropriate to
choose software such as Stata or Gauss which enables
programming.
iii) At the substantive level, the outputs obtained by ITCEQ and
DEFI experts are worthy of interest and open numerous avenues
for the development of Tunisia’s economic model and provide
responses to the challenges facing the Tunisian economy.
The modelling of micro manufacturing sectors based on approaches
to computable general equilibrium models has given rise to the
estimation of parameters, leading to the following conclusions:
- Substitution between capital and labour is high (elasticity close
to unity, Cobb-Douglas), in the food and agriculture sector as
well as in the Mechanical and Electrical Industries (sectors 2 and 4),
both of which are highly export-driven. Substitution between
both factors is lower (elasticity close to 0.7, CES) in the MCCV
and Chemicals sectors. In other sectors, there is complementarity
between factors of production;
Dynamic simulations show that the Tunisian industrial sectors
are characterized by a relatively high rigidity in the adjustment
of factors: in the wake of demand or actual cost shocks, it
generally takes three to four years for a significant adjustment
to occur in the quantity of labour and capital;
- The global productivity growth rate of factors is heterogeneous.
It is relatively low in IAA and textiles and high in IME and the
chemicals industry;
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- In all the sectors studied, there is a high elasticity of substitution
between skilled and unskilled employment14 ranging from
3.3 for sector 5 to more than 6 for sector 4. This outcome is
significant, apparently robust and relatively unexpected: It implies
in particular that a 1% decrease in the relative wage of skilled
workers versus unskilled workers would lead (in the long run) to
an increase in the number of jobs for skilled workers higher than
that of unskilled workers by 3% to 6%;
Consequently, these initial findings allow for the validation of both
the theoretical and econometric methodologies implemented. Hence,
based on the work done in this study, sector estimates of prices
and foreign trade - which still have to be done - must be conducted
without major difficulties.
iv) The findings of the estimates of export functions by sector,
conducted on time series data, provide important lessons, as
they highlight huge differences among sectors, both with respect
to the long-term price elasticities of the various sectors (and
hence their level of substitutability on the European market), and
to the dynamic behaviour of Tunisian exports in the wake of
relative price shocks and demand shocks (see Appendix).
Henceforth, the estimation of an aggregate export equation, even
if it meets econometric quality criteria, cannot underpin forecasts
and the formulation of a coherent industrial development policy.
The data panel estimates helped to meaningfully supplement the
estimates made for each sector considered separately.
Given the low number of observations in the sample studied, data
panel estimation allows for a rather robust estimation of the
'average' dynamic behaviour of sector exports. It follows that,
whatever the specifications used for the measurement of relative
prices:
- The elasticity of Tunisian exports to Europe in relation to expressed
demand is close to unity in the long run (this unit value is not
statistically rejected in ECMs), but, on average, seems relatively
low in the short term and even non-significant in growth rate
estimates. As a result, the instantaneous effect of a variation in
expressed demand may be considered negligible, given that
sector export adjustments probably require a time frame
substantially greater than 1 year;
- The price elasticity of Tunisian exports to Europe stands at -0.6
to -0.73 both in the short and long terms; and
- Lastly, the residual plots of the various models estimated suggest
that the IAA, IMCCV (the first sub-period) and hydrocarbons
sectors are the least close to the overall estimate, which justifies
the sector approach. Indeed, the time series data reveal that the
hydrocarbons sector has much higher price elasticity than other
sectors, while the IAA sector has relatively high short-term
demand elasticities compared to other export sectors
v) The project allowed ITCEQ experts to refine their knowledge of
Tunisia's specialization in international trade. The analysis of
Tunisia's competitor countries, through access to international
databases and the application of the outcomes of international
trade theory incorporated into the software "Swift Trade" was
strengthened. The dynamic positioning of Tunisia with respect
to global demand and the identification of competitor countries
are now available at the HS6 commodity classification level;
vi) Under the project, labour productivity of Tunisian businesses in
the industrial sector was analysed between 1997 and 2007, from
a sample of individual firms from annual surveys. The key findings
of this analysis are as follows:
14 It should be noted that the distinction between skilled/unskilled workers here is understood in terms of degree and not the type of business: in our estimates, skilled workerswere defined as higher education graduates, while the unskilled comprise other individuals. The terms used in our presentation ("skilled workers" and "unskilled workers") aretherefore deliberately simplistic and highly schematic.
56
First, the aggregate labour productivity of Tunisian businesses rose
sharply. It increased by 25% between 1997 and 2006 (and by 49%
between 1997 and 2007, although the past year should be considered
with extreme caution, given that 30% of the sample was renewed).
Second, at the sector level, aggregate labour productivity increased
in seven industries (food and agriculture, leather and footwear, timber,
paper and publishing, non-metal materials, metal materials, electrical
machinery and furniture). However, if year 2007 is disregarded,
aggregate productivity fell in five sectors (textiles, apparel, chemicals
and pharmaceuticals, rubber, plastics and automotive).
Third, while unweighted average productivity throughout the period
is higher for "large" firms than for "average" ones, aggregate
productivity grew faster for "medium"-sized businesses than for
"large" firms. From 2003 until 2006, the aggregate labour productivity
of "average" businesses exceeds that of “large” ones.
Fourth, the aggregate labour productivity of domestic firms rose
more sharply than those of companies with at least part of their
capital held by foreign investors.
Lastly, the decomposition results highlighted the role of resource
reallocation from less efficient to more efficient businesses in
boosting aggregate labour productivity across the entire sample.
The 25% productivity growth rate between 1997 and 2006 is
accounted for by 8% in labour productivity growth within
businesses and 17% from the reallocation effect. This is true
especially for domestic firms and "medium-" and "large-"sized
firms. However, at the sector level, this result is only true for two
industries (footwear and leather, and metal materials). Labour
productivity growth within businesses involved a larger number
of sectors (agri-food, textiles, timber, paper and publishing,
chemicals and pharmaceuticals, rubber and plastics, non-metal
materials, electrical machinery and furniture).
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Chapter I
Sector Modeling of Manufacturing Industries
in Tunisia
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Table of Contents
59 Introduction
61 1. Theoretical Foundations
62 1.1 The ‘unit price of value added’: definition
62 1.2 Demand for Factors
63 1.3 Demand foe Skilled and Unskilled Labour
63 1.4 Determining the Price of Value Added
64 1.5 Apportioning Supply between Exports and Supply of Goods on the Domestic Market
65 1.6 Apportioning Demand between Imports and Domestic Goods
65 1.7 Determining the Price and Volume of Exports
66 1.8 Defining Equations
66 1.9 Defining Equations
68 2. Equations f the Model
68 2.1 List of Variables and Parameters of the Model
69 2.2 Log-linear Equations (long-term relations)
70 2.3 Equations in Levels
72 3. Econometric Estimations72 3.1 List of Variables and Parameters of the Model72 3.1.1 Employment, Capital and Price of Value Added74 3.1.2 Skilled and Unskilled Employment
75 3.2 Data 21
75 3.3 Estimation Method
75 3.4 Key Findings77 3.4.1 Employment, Response to a Demand and Cost Shock79 3.4.2 Capital Response to a Demand and Cost Shock
81 Conclusion
82 Bibliography
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Introduction
In this paper, the modelling of a sector i producing a compositegood i is considered. This composite good can be either sold on
the domestic market or exported. Similarly, end users can purchase
this good on the domestic market from a sector i or import it.
The theoretical structure of the model hinges on principles widely
used in computable general equilibrium models (see Lofgren et al.,
2002):
Sector i is subject to the constraint of a two-factor production function
(labour L and capital K) of type CES, whose unit costs (respectively
W and Ck) are given at the sector level.
Production (QX = Y/iva, where iva represents value added in volume
per unit produced) from sector i is distributed between domestic
market sale (QD) at price Pd and export sale (QE) at price Pe. The
optimal distribution of production (QX) depends on the relative
price (Pd/Pe).
The proposed model quite naturally helps to consider as special
cases sectors whose production is intended solely for exports, or
alternatively, sectors whose production is entirely destined for the
domestic market.
Intermediate consumption is a constant fraction (ci) of the quantity
produced.
With respect to end users, the domestic absorption of goods typically
produced by sector i (QQ) is broken down between domestic sector
production (QD) and similar import products (QM). The absorption
distribution between both components depends on the relative price
of domestic products (Pd) with respect to the price of imported
products (Pm).
As concerns the conventional specifications of computable general
equilibrium (CGE) models, the peculiarities of this model are as follows:
- First, it is considered that the sector is subject to a demand
constraint on the goods market , so that optimal demand for
production factors (K and L), is realized under the constraint of
a given demand (Y / iva), which is determined by other sources
such as the level of domestic absorption (QQ),. Therefore, it is
essentially a demand model and not a supply model;
- Second, a distinction is introduced, within the labour factor (L),
skilled labour (Lnq), unskilled labour (LNQ),. Each of these two
types of labour characterized by a specific productivity index ,
as well as an own wage rate (Wq and Wnq respectively), assumed
to be exogenous in the sector; and
- Third, a foreign export demand is introduced, which determines
the export equilibrium price (Pe), whereas it is generally assumed
to be exogenous in the CGE models.
Section I presents the long-term linearized equations, whose
theoretical underpinnings are explained in Section II.
Indeed, the CGE models have the advantage of offering high internal
consistency, thus involving long-term solutions that may be
considered theoretically satisfactory. In return, these models generally
do not provide a description of the dynamic adjustment process
towards long-term solutions.
From this viewpoint, it is suggested in Section III that the estimation
of model equations be conducted within the broader dynamic
framework of error-correction equations.
For purposes of illustration, consider the equation for determining
60
the price of value added pyit (in logarithms):
pyit = π0 (ckit ― gki.t) + (1― π0) (wit ― qli.t) + py015 (23’)
where:
gki;: autonomous capital productivity growth rate;
qli: autonomous labour productivity growth rate.
The econometric estimation may be conducted in 2 stages:
1. Estimation of long-term relation:
pyit = π0 (ckit ― gki.t) + (1― π0) (wit ― qli.t) + py0 + Zt
2. Estimation of error-correction model:
∆pyit = a0 + a1∆pyit-1 +a2∆ckit +a3∆wit ― bZt-1 + εt
Where: ∆xt: variation of xt (the latter being expressed in logarithm).
Naturally, the lag order of explanatory variables will be determined
by conventional econometric criteria.
This type of specification is used to display short-term elasticities
(a2, a3) subsequently different from long-term elasticities (π0 and1― π0 in our example).
In addition, it helps to measure the adjustment speed towards long-run
equilibrium (which is related to parameter b), the latter being conditioned
by the various bottlenecks affecting the functioning of markets.
The advantage of the error-correction model is that it guarantees
convergence towards long-run equilibrium (provided that the empirical
results confirm the validity of equation 23 in our example), -
symmetrically - The Granger representation theorem states that a
long-term relationship (as defined in the cointegration theory),
necessarily admits representation in the form of ECM.
Following this methodology, which is particularly preferred in the
macroeconomic model of the Bank of England16, it is therefore possible
to propose and estimate a sector modelling that is both theoretically
coherent and consistent with observable dynamic processes.
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15 Lower case letters designate variables in logarithm16 This involves implementing the usual unit root tests, e.g. Dickey and Fuller (1981).
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1. Theoretical Foundations
Assume that each sector i produces a composite good i. The
model seeks to determine the long-term equilibrium quantities
and prices, based on the principles used in computable general
equilibrium models. In the theoretical model, the sector index (i), will
be omitted to simplify the notations.
1.1 The 'unit price of value added’: definition
Value added in value is decomposed according to:
Pyt Yt = Wt Lt + Ckt Kt (1)
where:
Py: price of value added of the sector
Y: value added in volume of the sector
W: average wage rate of the sector
L: employment of the sector
Ck: capital cost of the sector
K: capital stock of the sector
and the sector decomposition of production in value is written as
follows:
Pxt QXt = Pyt Yt + Pcit CIt + TAXt ― SUBVt (2)
where:
QX: production in volume of sector i
Px: production price of the sector
Pci: unit price of intermediate consumption of the sector
CI: quantity of intermediate consumption
TAX: taxes paid
SUBV: subventions received
Let:
CIt = ci.QXt
where ci is the intermediate consumption coefficient
SUBVt = sv.QXt (3)
where sv is the amount of subventions received per unit produced
TAXt = tva.pyt.Yt (4)
where tva is the value added tax rate
Yt = iva.QXt
where iva is the value added in volume per unit produced
The ‘price of value added’ of sector (Py) is defined below by the
expression:
Pyt = [Pxt ― Pcit ci + sv] / [iva (1+tva)] 5)
Given that the price of value added (Py) is subsequently determined
based on marginal costs, this expression helps to define the sector’s
unit production price:
62
Pxt = Pyt iva (1+tva) + ci Pcit ― sv (6)
Intermediate consumption of sector (i) may be disaggregated
depending on their sector of origin (j), which implies:
CIt = QXt SOMME(ci[j]) (7)
and consequently:
ci = SOMME(ci[j]) (8)
Pcit = SOMME(Pqt [j] ci[j]) / ci (9)
1.2 Demand for Factors
The technical constraint of production is a CES standardized
production function (cf. particularly Klump et al., 2008):
(10)
where:
Y0 , L0 , K0 : value added in volume, employment and capital stock
at reference date t=0
Alt , Akt : labour and capital productivity indices
π0 = Ck0 K0 / Py0 Y0: share of capital remuneration in value addedat reference date
Py0 Y0 = Ck0 K0 + W0 Y0: value added at reference date
First-order conditions for the optimum lead to the following relation:
Kt / Lt =( Akt /Alt ) σ − 1 (Ckt / Wt) − σ (K0 / L0) 1 − σ [π0/(1- π0)] σ
Capital Stock and Investment
If businesses are subject to a demand constraint (Y given), the stock
of capital deduced from the production function and optimum
condition will be:
(11’)
The log-linear approximation of this equation may be expressed
as follows:
kt = yt ― σ (ckt ― wt) + (σ― 1) gk.t + k0 (11’)
where Ckt is the cost of capital utilization based on Hall-
Jorgenson:
Ckt = Pkt (it+1 ― pk’t+1 + δ) (12)
with:
Pk: investment price,
i: nominal interest rate,
δ: capital depreciation rate,
pk’: capital price rate of change.
Given the capital stock evolution equation:
Kt = It + (1―δ).Kt-1 (13)
Optimal investment will be:
It = Kt ― (1―δ)Kt-1 (14)
It will suppose that independent capital productivity follows a
deterministic trend:
Akt = (1+gk)t (15)
Demand for Labour
Market-constrained demand for labour is written as follows:
(16)
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Which is expressed in logarithms as:
lt = yt ― σ (wt ― pyt) + (σ ― 1)gl.t + l0 (16’)
It will suppose that independent labour productivity follows a
deterministic trend:
Alt =(1+gl)t (17)
1.3 Demand for Skilled and Unskilled Labour
Total employment is supposed to be a CES combination of skilled
labour (Lq) and unskilled labour (Lnq):
(18)
where:
Alqt, Alnqt: skilled and unskilled labour productivity index
γ0 = Wnq0 Lnq0 / W0 L0: share of unskilled labour remuneration in
total remuneration at reference date
W0 L0 = Wnq0 Lnq0 + Wq0 Lq0: wage bill at reference date
At the optimum, demands for skilled and unskilled labour are
respectively written as follows:
Lnqt = Lt (Alnqt / Alt)κ−1 (Wnqt /Wt ) −κ (Wnq0 /W0 ) κ−1 γ0 (19)
Lqt = Lt (Alqt/ Alt) κ−1 (Wqt/Wt)−κ(Wq0/W0) κ−1 (1-γ0) (20)
where:
Wnq: unskilled wage rate
Wq: skilled wage rate
It is supposed that the independent labour productivity of each type
follows a deterministic trend:
Alnqt =(1+glnq)t (21)
Alqt =(1+glq)t (21a)
Hence, the log-linear equations of demands for unskilled and skilled
labour are respectively written as follows:
lnqt = lt ― κ (wnqt ― wt ) + (κ ―1)( glnq ― gl).t + lnq0 (19’)
where glnq.t is a trend term that measures the independent
productivity of unskilled labour.
lqt = lt ― κ (wqt ― wt ) + (κ ― 1)( glq ― gl).t + lq0 (20’)
where glq.t is a trend term that measures the independent productivity
of skilled labour.
The average wage rate of the sector will be a combination of skilled
and unskilled wage rates:
(22)
From where the following log-linear equation is deduced:
wt = (1―π0)(wqt ― glq.t) + π0 (wnqt ― glnq.t) + gl.t + w0 (22’)
1.4 Determining the Price of Value Added
Given the accounting relation (equation 1):
Pyt Yt = Wt Lt + Ckt Kt
where Y is production of the sector, W is the average wage bill of
the sector, L is the total employment level of the sector (equation
16), Ck is the cost of capital utilization (given in equation 12) and K
is the capital stock (equation 11).
The price of value added is deduced from the optimal demand of
factors:
64
(23)
which leads to the following log-linear approximation:
pyt = π0 (ckt ― qk.t) +(1― π0) (wt ― ql.t) + py0 (23’)
1.5 Apportioning Supply between Exports andSupply of Goods on the Domestic Market
Domestic production in value of sector i is decomposed in exports
in value and domestic production in value:
Px t (Y t / iva) = Pet QEt + Pdt QDt (24)
where:
Px: total production price of sector i
Y / iva: total production of sector i
Pe: export price of sector i
QE: exports supply of sector i
Pd: price of goods of sector i on the domestic market
QD: supply of goods on the domestic market of sector i
If domestic production:
- Is not sold on the domestic market: Y/iva = QE
- Is not sold for export: Y/iva = QD
The processing function of domestic production between the two
destinations is written as follows (cf Annabi et al., 2003):
(25)
Where:
Y0 / iva,QD0 , QE0 : total production of sector i, supply of goods on
the domestic market of sector i and exports supply of sector i at
reference date t=0
μ0 = Pe0 QE0 / (Py0 Y0 / iva): share of exports in value in the production
of sector i at reference date
Px0 Y0 / iva = Pd0 QD0 + Pe0 QE0: production in value at reference
date
-∞ < π < 0: processing elasticity
At the optimum, the maximization of revenue (24), constrained by
the processing function (25), helps to determine the supply of exports
and the supply of goods on the domestic market:
QEt = (Yt / iva) (Pet / Pxt) ―π(Pe0 / Px0) π ― 1 μ0 (26)
QDt = (Yt / iva) (Pdt / Pxt) ―π(Pd0 / Px0) π ― 1 (1-μ0) (27)
Let:
qet = yt + π (pxt ― pet) + qe0 (26’)
qdt = yt + π (pxt ― pdt) + qd0 (27’)
with π<0
and production price is deduced from the optimal apportioning of
supply:
Given that production price (Px) is determined based on the price
of value added (equation 6) and that the export price is determined
by balancing supply and export demand (equation 37), the expression
of the price of good i on the domestic market may be deduced from
this equation:
which leads to the following logarithmic approximation:
pdt = [ 1/ (1― μ0)]pxt ― [μ0/ (1― μ0)] pet + pd0 (28’)
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1.6 Apportioning Demand between Imports andDomestic Goods
Domestic absorption in value for good i is decomposed in imports
in value and domestic production in value:
Pqt (1―tq) QQt = Pmt QMt + Pdt QDt (29)
where QQ is domestic absorption (sum of public and private
consumption, investments, intermediate consumption), tq is tax
rates, Pm is the price of import goods of sector i and QM is the
volume of good imports of sector i.
The Armington aggregation function of absorption between both
components is written as follows (cf Annabi et al., 2003):
where:
QQ0, QD0 , QM0 : total absorption of goods i, demand for goods i
on the domestic market and demand for imports i at reference
date t=0
λ0 = Pm00 QM0 / [Pq0 (1―tq0) QQ0]: share of imports in value in the
absorption at reference date
Pq0 (1―tq0) QQ0 = Pd0 QD0 + Pm0 QM0: absorption in value at
reference date
∞ > α > 0: substitution parameter
If good i:
- Is not produced on the domestic market: QQ = QM
- S not imported : QQ = QD
The minimization of total cost (30), constrained by the Armington
function, implies that at optimum, the demand for imports and for
goods i on the domestic market will respectively be:
QMt = QQt (Pmt / Pqt (1―tq)] ―α [Pm0 / Pq0 (1―tq0)]α ―1 𝜆0 (31)
QDt = QQt [Pdt / Pqt (1―tq)] ―α [Pd0 / Pq0 (1―tq0)]α ―1 (1― 𝜆0) (32)
or, in the form of logarithm:
qmt = qqt ― α (pmt ― pqt + tq) +qm0 (31’)
qdt = qqt ― α (pdt ― pqt + tq) + qd1 (32’)
And the absorption price is deduced from the optimal apportionment
of absorption:
(33’)
which implies the following log-linearized equation:
pqt = tq + α0(pmt ― pdt) + pdt + pq0 (33’)
1.7 Determining the Price of Quantities traded onthe Domestic Market
The price and quantities traded on the domestic market are deduced
from equations 27 and 32.
The quantities of good i traded on the domestic market as a result
of balancing supply and demand are given in the following equation:
QDt = (Yt /iva) α /(α ―π) QQt―π /(α ―π) (Pxt / Pqt (1-tq)] α π /(α ―π) C1 (34)
where: C1 = [(1― π0) ―π /(α―π) (1―μ0) α /(α―π) Px0 α (π ― 1) /(α ― π) [Pq0
(1―tq0)] ( 1― α)[ ―π /(α―π)] ] / Pd0
which gives the log-linear equation:
qdt = [α /(α ― π)] yt ― [π /(α ― π)]qqt + [α π /(α ― π)] (pxt ―
pqt + tq) + d0 (34’)
The equilibrium price of good i on the domestic market resulting
from the equalization of supply and demand is as follows:
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Pdt = (iva QQt / Yt ) 1/(α ― π) [Pqt (1-tq)]α /(α ―π) Pxt ―π /(α ―π) C0
where:
C0 = Pd0 Px0 (π ―1) /(α ―π) [Pq0 (1―tq0)]( 1― α)/(α ― π) [(1― π0)/(1―μ0)][1/(α ― π)
Since the definition of domestic price is given in equation (28), the
volume of value added (Y) can be determined to meet the equilibrium
of good i on the domestic market:
(35)
where: C2 = [(1―π0)/(1―μ0)] [Pq0(1―tq0)]1―α Px0π―1
i.e., by linearizing:
yt = qqt + α(pqt - tq) ― π pxt + (π ― α)pdt + y0 (35’)
1.8 Determining the Price and Volume of Exports
Assuming that foreign demand (QE) for goods of sector i is expressed
as follows:
QEt = cx Y*t [(1― te) EXR P*t / Pet] π (36)
where Y*t is foreign income and P*t is the foreign price index
(expressed in foreign exchange units, FCU).
The ratio Pe / [(1 ― te) EXR] helps to convert the export price into
foreign currency units, and takes into account current import taxes
on export markets (te).
which can be expressed in logarithms as follows:
qet = cx0 + y*t + π (p*t + exrt ― te ― pet) (36’)
The export price is deduced from equations 26 and 36 which helps
to balance supply with demand for exports, as well the equilibrium
export volume:
Pet = Pxtπ / (π ―π) [P*t EXR (1― te)] ―π / (π ― π) [(μ0 Yt) / (cx iva Y*t)]1/(π―π)
(Pe0/Px0) (π ― 1) / (π ―π) (37)
QEt = [Pxt / (P*t(1-te)EXR )] ―π π / (π―π) (cx Y*t) π / (π―π) (μ0 Yt / iva ) ―π / (π―π)
(Pe0/Px0)π (1 ― π) / (π ―π) (38)
i.e., in logarithms:
pet = [ π / (π ― π)]pxt ― [ π / (π ― π)] (p*t + exrt ― te) + [1/
(π ―π)] (yt ― y*t) + pe0 (37’)
qet = ― [π π / (π ― π)] [pxt ―(p*t + exrt ― te)] +[ π /(π ―π)]
y*t ― [ π /(π ―π)] yt + qe0 (38’)
1.9 Defining Equations
Import Prices
Pmt = Pwmt (1+tm).EXRt (39)
Pm: import price of good i LCU
Pwm: import price of good i FCU
tm: import tax rate of good i
EXR: exchange rate LCU to FCU
i.e., in logarithms:
pmt = pwmt + tm + exrt (39’)
Export price in foreign currency (FCU)
Pwet = Pet / (1―te).EXRt (40)
Pe: export price of good i in local currency (LCU)
Pwe: f.o.b. export price of good i in foreign currency (FCU)
te: export taxes of good i (levied by importing countries)
EXR: exchange rate LCU to FCU
i.e., in logarithms, the expression of export price in local currency:
pet = pwet ― te + exrt (40’)
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Domestic demand for composite good i:
QQti = Cti + SOMME(Ijti) + GOVti (41)
where:
Ci: final consumption of goods i
Iji: investment of sectors j in goods i
GOVi: public expenditure in good i
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2. Model Equations
2.1 List of model variables and parameters
Structural parameters are presented in Greek characters or
in lower-case, unsubscripted letters. The same applies for
economic policy parameters.
Endogenous Variables
Py: price of value added of the sector
Y: value added in volume of the sector
W: average wage rate of the sector
L: total labour of the sector
Lnq: unskilled employment of the sector
Lq: skilled employment of the sector
K: capital stock of the sector
QX: production in volume of the sector
Px: production price of the sector
CI: quantity of intermediate consumption used in the sector
TAX: taxes paid in the sector
SUBV: subventions received by the sector
Px: total production price of the sector
Pe: export price of goods i
QE: exports in volume of the sector
Pd: price of good of sector i on the domestic market
QD: sales in volume of goods on the domestic market of the sector
Pm: import price of good i in local currency (LCU)
Pe: export price of good i in local currency (LCU)
Pwe: f.o.b. export price of good i in foreign currency (FCU)
QM: imports in volume of goods i
Exogenous Variables (in the sector)
Wnq: unskilled wage rate
Wq: skilled wage rate
Pci: unit price of intermediate consumption in sector i
QQ: domestic absorption in volume (sum of public and private
consumption,
investments, intermediate consumption) in goods i
Y*t: foreign income
P*t: foreign price index (in foreign currency).
Pwm: import price of good i in foreign currency (FCU)
EXR: exchange rate (local currency LCU to foreign currency FCU)
te: export tax rates of good i (levied by importing countries)
Alt , Akt : labour and capital productivity index
Alqt , Alnqt : skilled and unskilled labour productivity index
Ckt: capital cost of the sector, decomposed as follows:
Pkt: investment price,
it: nominal interest rate,
pkt’: capital price rate of change.
Economic Policy Parameters
tq: production tax rate of good i
tm: import tax rate of good i
sv: subventions received per unit produced
tva: value added tax rate
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Structural Parameters
δ: capital depreciation rate,
∞ > σ > 0: substitution elasticity between capital and labour
(production function)
∞ > κ > 0: substitution elasticity between unskilled employment and skilled employment (aggregation function)
-∞ < π < 0: processing elasticity (processing function)
∞ > α > 0: substitution parameter (Armington function)
-∞ < - π < 0: foreign demand price elasticity
ci: intermediate consumption coefficient
iva: value added per unit of volume produced
2.2 Log-linear Equations (long-term relations)
The level variables are represented in uppercase letters and variables
in logarithms in lower case.
Latin letters indexed by a 0 (e.g. x0) represent the constant terms
of long-term regression equations, while the Greek letters represent
the structural parameters of the theoretical model.
The numbering of the equations refers to those of the theoretical
model presented in Chapter II.
Capital stock of the sector:
kit = yit ― σ (ckit ― pyit) + (σ−1) gki.t + k0 (11’)
where: Ckit is the cost of capital utilization based on Hall-
Jorgenson:
Ckit = Pkit (it+1 ― pk’t+1 + δ) (12)
with:
Pk: investment price,
i: nominal interest rate,
δ: capital depreciation rate,
pk’: capital price rate of change.
and gki measures the rate of change of independent capital
productivity.
Total employment of the sector:
lit = yit + σ (wit ― pyit) + (σ ― 1)gli.t + l0 (16’)
where gli measures the rate of change of independent labour
productivity.
Unskilled employment of the sector:
lnqit = lit ― κ (wnqit ― wit ) + (κ ―1)( glnqi ― gli).t + lnq0 (19’)
where:
glnq measures the rate of change of independent unskilled labour
productivity.
wnq is the unskilled wage rate
Skilled employment of the sector:
lqit = lit ― κ (wqit ― wit ) + (κ ― 1)( glqi ― gli).t + lq0 (20’)
where:
glq measures the rate of change of independent skilled labour
productivity.
wq is the skilled wage rate
Average wage rate of the sector:
wit = (1―π0)(wqit ― glqi.t) + π0(wnqit ― glnqi.t) + gli.t + w0 (22’)
Price of value added of the sector:
pyit = π0 (ckit ― gki.t) + (1― π0) (wit ― gli.t) + py0 (23’)
Price of goods sold on the domestic market:
70
pdit = [ 1/ (1― μ0)]pxit ― [μ0 / (1― μ0)] peit + pd0 (28’)
Absorption price of good i:
pqit = tqi + π0 (pmit ― pdit) + pdit + pq0 (33’)
Import volume of good i:
qmit = qqit ― α (pmi
t ― pqit + tqi) + qm0 (31’)
where qq is the domestic absorption of good i
Sales volume of sector i on the domestic market:
qdit = [α /(α ― π)] yit ― [π /(α ― π)]qqit + [α π /(α ― π)] (pxit ―
pqit + tqi) + d0 (34’)
Value added of the sector:
yit = qqit + α(pqit - tqi) ― π px it + (π― α)pd it + y0 (35’)
Export sales price of sector i:
peit = [ π /(π ― π)] pxit ― [ π /(π ― π)] (p*t + exrt ― te)+ [1/(π ―π)]
(yit ― y*t) + pe0 (37’)
where:
p* : foreign price index
y* : real foreign income index
Export volume of sector i:
qeit = ― [π π /(π ― π)] (pxit ― p*t ― exrt + te) + [ π / (π ―π)] y*t
― [ π / (π ―π)] yit + qe0 (38’)
Defining Equations
Import prices of goods i:
pmit = pwmi
t + tmi + exrt (39’)
Export prices of goods of sector i in foreign currency (LCU):
pweit = peit + tei - exrt (40’)
2.3 Level Equations
Intermediate consumption of sector i:
CIit = cii QXit
where ci is the intermediate consumption coefficient
Subventions received by sector i:
SUBVit = svi QXit (3)
where sv is the amount of subventions received per unit
produced
Taxes paid by sector i:
TAXit = tvai pyit Yit (4)
where tvai is the value added tax rate
Total production volume of sector i:
QXit = Yit / ivai
where iva is the value-added volume per unit produced
Production price of sector i:
Pxit = Pyit ivai (1+tvai) + cii Pciit ― svi (6)
Intermediate consumption of sector (i) disaggregated by sector of
origin (j):
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CIit = QXit SOMME(cii [j]) (7)
And consequently:
cii = SOMME(cii [j]) (8)
Pciit = SOMME(Pqit [j] cii [j]) / cii (9)
Investment of sector i:
Iit = Kit ― (1―δ)Kit-1 (14)
Domestic demand for composite good i:
QQti = SOMME(CIjit) + Cti + SOMME(Ijti) + GOVti (41)
where:
CIji: intermediate consumption by sectors j of goods i
Ci: final consumption of goods i
Iji: investment by sectors j on goods i
GOVi: public expenditure on good i
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T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Capital stock of sector i:
kit = yit ― σ (ckit―pyit) + (σ―1) gki.t + k0 (11’)
Total employment in sector i:
lit = yit +σ (wit―pyit) + (σ―1)gli.t + l0 (16’)
Price of value added of sector i:
pyit = π0 (ckit―gkI.t) + (1―π0) (wit―gli.t) + py0 (23’)
where:
kit volume of capital stock of sector i (logarithm)yit volume of value added of sector i (logarithm)(ckit � pyit) cost of capital utilization of sector i in real terms (logarithm)gki annual capital productivity growth rate of sector i lit number of hours worked in sector i (logarithm)(wi
t � pyit) actual wage rate in sector i (logarithm)gli annual labour productivity growth rate in sector ipyit value added price index of sector i (logarithm)
Table 1: Estimated factor demand equations (long term)
As is mentioned in Table 1, the econometric estimation is performed
on the logarithm of the various model variables (capital, employment,
wages, cost of capital, price of value added).
Regarding the calculation of the cost of using capital (ckit), two
measures were tested:
- The first is to calculate the cost of using capital as defined in
Hall-Jorgenson (i.e. by calculating the sum of real interest rate
and capital depreciation rate); and
- The second uses the unit cost of using capital, derived from the
accounting allocation of value added.
Based on equations derived from the theoretical model, this
section presents the estimation of the production block of
the Tunisian manufacturing industry decomposed into six sectors.
The estimated equations are firstly those regarding total
employment, capital stock, price of value added, and secondly,
those pertaining to employment, broken down into skilled and
unskilled workers.
III.1 Estimated equations
3.1.1 Employment, capital and price of value added.
We conducted the estimation of factor demand functions arising from
the CES production function (equation 10). This amounts to estimating
the demand for capital equations (equation 11'), labour (equation
16') and the price of value added (equation 23’) (Table III.1).
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Among these two possible specifications, the second proved to be
much more relevant and it was therefore chosen for the purpose of
the estimates.
Second, it is worth noting that employment (lit) can be measured in
two ways:
- Either in terms of stock, i.e. by retaining the number of people
employed;
- Or, in terms of flows, by retaining the total number of hours
worked (hours per person multiplied by the number of people
employed).
To best measure the impact of a wage change, the second of these
measures was selected: indeed, following a change in the relative
cost of labour, firms may be led to modify the number of employees,
or the average number of hours worked.
Lastly, it is worth noting that each production factor is supposed
to assume the growth rate of its own productivity (gki measures the
rate of change of independent capital productivity and gli measures
the rate of change of independent labour productivity in each sector
i). In accordance with standard practice, it is assumed that growth
rate is constant over time, which means that in the long run, the
'technical progress' incorporated into factors follow a deterministic
trend.
Regarding the estimation of such growth rates of technical progress
(respectively denoted gl and gk), three types were tested: the first
is that of a neutral technical progress as defined by Harrod, i.e. it
only increases work efficiency (gl > 0 and gk = 0). The second is
that of technical progress which only increases the efficiency of
capital (neutrality as defined by Solow, gl = 0 and gk > 0). A final
form induces an increase common to both factors (Hicks-neutral,
gl = gk > 0).
As presented in Table III.1, the estimated equations represent long-
term relationships, provided the usual conditions for cointegration
are met (the variables of the models must be integrated to order 1
and residuals of equations integrated to order 0).
From this point of view, one of the objectives of the estimate is to
assess the long-term sensitivity of capital stock trend and
employment levels to changes in real factor costs (wages and cost
of capital), through the estimation of elasticities of substitution (σ)
between capital and labour, in each sector under review. Thus, a
high elasticity of substitution will lead to a substantial increase in the
capital/labour ratio as a result of an increase in the relative price of
factors (salary/cost of capital).
To take into account the dynamics of the model in the shorter term,
i.e. outside the long-run equilibrium, the additional parameters of the
model were estimated under an error-correction model- ECM (Table 2).
Capital stock of sector i:Notation: Δxt = xt ― xt-1
Capital stock of sector i:Δkit = a0 + a1Δ yit + a2Δ yit-1 + a3Δ(ckit ― pyit) + a4Δ(ckit-1 ― pyit-1) + a5Δ kit-1
― γk [ kit ― yit + σ (ckit ― pyit) ― (σ ― 1) gki.t ― k0] + εkt
Total Employment in sector i:Δli
t = b0 + b1Δ yit + b2Δ yit-1 + b3Δ(wit ― pyit) + b4Δ(wi
t-1 ― pyit-1) + b5Δ lit-1― γl [ lit ― yit ― σ (wi
t ― pyit) ― (σ ―1) gli.t ― l0] + εlt
Price of value added of sector i:Δpyit = c0 + c1Δ ckit + c2Δ ckit-1 + c3Δwi
t + c4Δwit-1 + c5Δpylit-1
― γp [pyit ― π0 (ckit ― gki.t) ― (1― π0) (wit ― gli.t) ― py0] + εpt
Table 2: Factor Demand Equations estimated (ECM)
74
The equations presented in Table 2 represent the form being
tested in all generality. To improve the specification, parameters not
significantly different from zero were not retained in the final model,
and some dummy variables were introduced.
In its current form, the ECM model is a significant asset for the
dynamics: short-term elasticities (coefficients a1, a2, …. , a5 ; b1, b2,
…. , b5 ; c1, c2, …. , c5) may be introduced, and differ from long-
term elasticities (σ, π0 ,…).
Similarly, the error-correction model helps to measure buoyancy (γk, γl,
γp) toward long-run equilibrium, i.e. the proportion of a deviation in the
long run may be absorbed in a given period: given that the elementary
period here is one year, it is expected that these coefficients are close
to unity if the dependent variable is not characterized by strong viscosity.
3.1.2. Skilled and unskilled employment
In addition, the demand for skilled/unskilled labour was estimated
(equations 19 and 20 of the theoretical model).
The objective here is to assess the short- and long-term impact of
a change in the relative wage on the structure of (skilled/unskilled)
employment.
At the theoretical level, companies benefit from using relatively
more skilled workers - in spite of higher wages - on condition that
they have productive characteristics distinct from those of unskilled
workers (or, in other words, that skilled and unskilled workers are
not close substitutes). In the opposite case, companies will benefit
from using cheaper labour.
As a result, the key parameter for measuring the impact of a change
in the relative wage on the employment structure will be the elasticity
of substitution between the two categories of employees.
Table 3 shows the two long-term employment demand equations
(only one which is estimated because of redundancy), and this
for each of the 6 manufacturing sectors: the elasticity of
substitution between skilled and unskilled workers κ is noted
therein.
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Unskilled employment in sector i:lnqit = lit ― κ (wnqit ― wi
t ) + (κ ―1)( glnqi ― gli).t + lnq0 (19’)
Skilled employment in sector i:lqit = lit ― κ (wqit ― wi
t ) + (κ ― 1)( glqi ― gli).t + lq0 (20’)
where:
glnq rate of change of independent unskilled labour productivitywnq unskilled wage rate glq rate of change of independent skilled labour productivitywq skilled wage rate
Table 3: Employment Demand Equations by Qualification (long term)
It should be noted that the distinction between skilled/unskilled
workers here is understood in terms of degree and not the type
of business: in our estimates, skilled workers were defined as higher
education graduates, while unskilled workers comprise other
individuals. The terms used in our presentation ("skilled workers"
and "unskilled workers") are therefore deliberately simplistic and
highly schematic.
To complete the estimation, long-term equations were once more
placed in the broader context of error correction models. The generic
form of the dynamic equations estimated is given in Table III.4. As
above, the non-significant short-term coefficients were removed from
the final equations.
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3.2 Data
The estimation period spans from 1983 to 2009. Data were collected
from the annual national accounts for the Tunisian economy. Six
manufacturing sectors are analysed, namely:
Sector 2: Agri-food Industry (IAA);
Sector 3: Ceramic Building Materials and Glass Industries (MCCV);
Sector 4: Mechanical and Electrical Industries (EMI);
Sector 5: Chemical Industries (CHEMISTRY);
Sector 6: Textile Apparel and Leather Industries (THC); and
Sector 7: Miscellaneous Industries (MISCELLANEOUS).
Before conducting the econometric estimation, the order of
integration of the series used was tested using the Augmented
Dickey-Fuller (ADF) test. The results show that the entire series tested
are all integrated to order 1.
3.3 Estimation Method
The low number of observations available (at most 27) and the
presence of common parameters to be estimated in the various
long-term equations (elasticities of substitution, the growth rate of
technological progress) prompted the simultaneous estimation of
these equations.
Consequently, the following two-stage process was adopted:
3. In stage one, long-term relationships were estimated, per level,
for equations 11’, 16’, 20’ and 23’ through a simultaneous
equations system using the SUR (Seemingly Unrelated
Regression) method.
4. In stage two, 4 ECMs (Error-Correction Models) were estimated
by imposing therein relations estimated in stage one as long-
term solution.
3.4 Key Outputs
Before commenting on the outputs, it is worth noting that all ECMs
have satisfactory statistical properties. LM tests result in the rejection
of the hypothesis of autocorrelation in the residuals of these
equations. These residuals are homoskedastic under the White test
and the ARCH test. The functional form of the equation passed the
Reset test. Lastly, according to the Jarque Bera test, the residuals
of all equations are normally distributed.
The key outputs are summarized in Table III.5:
• There would be a relatively high substitutability between capital
and labour in 4 sectors as follows: the elasticity of substitution
is close to unity in the Agri-food Industry as well as in the
Mechanical and Electrical Industry (sectors 2 and 4). The elasticity
of substitution is close to 0.7 in the Ceramic Building Materials
and Glass and Chemicals industries (sectors 3 and 5). However,
it is worth noting that the value of these elasticities is probably
Notation: Δxt = xt ― xt-1
Unskilled employment in sector i:Δlnqit = d0 + d1Δ lit + d2Δ lit-1 + d3Δ(wnqit ― wi
t) + d4Δ(wnqit-1 ― wit-1) + d5Δ lnqit-1
― γnq [ lnqit ― lit + κ (wnqit ― wit ) ― (κ ― 1)( glnqi ― gli).t ― lnq0 ] + εnqt
Skilled employment in sector i:Δlqit = g0 + g1Δ lit + g2Δ lit-1 + g3Δ(wqit ― wi
t) + g4Δ(wqit-1 ― wit-1) + g5Δ lqit-1
― γq [lqit ― lit + κ (wqit ― wit ) ― (κ ― 1)( glqi ― gli).t ― lq0] + εqt
Table 4: Employment Demand Equations by Qualification (ECM)
76
over-estimated by including working hours in labour. In other
words, this does not involve elasticity between capital and labour,
which is being estimated here, but between capital stock and
work hours.
• However, there seems to be a strong complementarity between
capital and labour in the last two sectors under review, namely
Textile, Apparel and Leather and miscellaneous industries (sectors
6 and 7). This implies that in these sectors, and unlike the previous
ones, a variation in the relative cost of labour relative to capital
will have little long-term impact on capital intensity (capital stock
per worker).
• As per our estimates, it seems that the formulation of a Hicks-
neutral technical progress is the only one to be accepted in the
6 sectors studied. In sectors 2, 6 and 7, the estimated growth
rate of technical progress (gk and gl parameters, which are
identical in the Hicks-neutral technology parameters) is between
1 and 2% per year. It is close to 2.7% in sector 4 and above
5% in sectors 3 and 5.
• In all the sectors studied, there is a high elasticity of substitution
between skilled and unskilled employment ranging from 3.3 for
sector 5 to more than 6 for sector 4. This outcome is significant,
apparently robust and relatively unexpected: It implies in particular
that a 1% decrease in the relative wage of skilled workers versus
unskilled workers would lead (in the long run) to an increase in
the number of jobs for skilled workers higher than that of unskilled
workers by 3% to 6%. In other words, a tighter wage gap
between skilled and unskilled workers would be, according to
this estimate, an effective means of improving the "employability"
of graduates. One possible interpretation of this result is that,
on average, graduates would not have enough specific expertise
that would suitably distinguish them from unskilled workers, given
that both categories are consequently considered by businesses
as substitutes rather than complements in the production
process.
• In conclusion, it should be recalled that long-term elasticities
with respect to quantities were fixed to unity, for obvious reasons
of theoretical consistency: thus, when the total amount of work
increases by 1%, the amount of hours put in by skilled and
unskilled workers increases identically by 1% (all things being
equal). Similarly, when demand for goods (measured by value
added in volume) increases by 1%, the amount of capital and
labour increases identically by 1%.
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Table 5: Main Outcomes for Sector Estimates
Sector 2 3 4 5 6 7
Structural Parameters
Elasticity of substitution K/L 0.99 0.74 0.98 0.67 0.06 0.14
Elasticity of substitution Skilled/Unskilled labour 5.40 4.10 6.01 3.29 4.67 5.55
Hicks-Neutral technical progress…
… (%) .1.97 5.11 2.68 5.28 1.06 1.67
ECM Parameters
Employment buoyancy 0.40 0.21 0.32 0.12 0.21 0.31
Capital buoyancy 0.05 0.13 0.07 0.06 0.14 0.04
Sources: National Accounting, ITCEQ/DEFI calculations
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To illustrate the dynamic process of the different variables and their
sensitivity to economic determinants, the assessment of sector
responses to some economic shocks was conducted.
3.4.1. Employment Response to Demand and CostShock
Two shocks were simulated:
1. The first is a 1% increase in value added
2. The second shock is a 1% increase in real wages
The outcomes of these simulations are summarized in Table 6 and
in the graphs below.
Table 6: Dynamic Response of a 1% VA and Real Wages (RW) Shock on Employment
T 1 year 2 years 3 years 4 years Long term
IAA VA 0.31 0.46 0.62 0.71 0.79 1
RW -1.16 -0.63 -0.97 -0.84 -0.94 -0.98
MCCVVA 0.85 0.88 0.38 0.52 0.62 1
RW 0 -0.77 -0.76 -0.75 0.74 -0.73
IME VA 0.44 0.62 0.74 0.82 0.88 1
RW -0.21 -0.46 -0.62 -0.73 -0.81 -0.97
CHEMI VA 0.19 0.30 0.28 0.31 0.32 1
RW -0.22 -0.06 -0.01 -0.20 -0.28 -0.67
THCVA 0.37 0.50 0.61 0.69 0.76 1
RW -0.47 -0.38 -0.31 -0.26 -0.21 -0.05
MISCEL VA 0.53 0.68 0.78 0.85 0.90 1
RW 0 -0.04 -0.07 -0.09 -0.11 -0.13
Sources: National Accounting, ITCEQ/DEFI calculations
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Graph 1: Employment variation (in %) following a 1% increase in value added
Graph 2: Employment variation (in %) following a 1% increase in real wages
3.4.2. Capital Response to Demand and Cost Shock
Two shocks were also simulated for capital:
3. A 1% increase in value added
4. A 1% increase in the real cost of capital.
The results of these simulations are summarized in Table 7 and in
the graphs below.
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Table 7: Dynamic Response of a 1% VA and actual cost (CKR) shock on Capital Stock.
T 1 year 2 years 3 years 4 years Long term
IAA
VA 0.318 0.51 0.71 0.83 0.91 1
RW -0.10 -0.27 -0.40 -0.50 -0.64 -0.98
MCCV
VA 0.17 0.36 0.58 0.78 0.93 1
RW -0.14 -0.29 -0.45 -0.61 -0.73 -0.73
IME
VA 0 0.18 0.42 0.65 0.83 1
RW 0 -0.07 -0.21 -0.39 -0.56 -0.97
CHEMI
VA 0 0.15 0.25 0.39 0.52 1
RW -0.03 -0.15 -0.24 -0.34 -0.43 -0.67
THC
VA 0.27 0.50 0.67 0.79 0.87 1
RW -0.008 -0.028 -0.036 -0.042 -0.047 -0.05
MISCEL
VA 0 0.04 0.10 0.17 0.24 1
RW -0.04 -0.07 -0.08 -0.09 -0.10 -0.13
Sources: National Accounting, ITCEQ/DEFI calculations
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Graph 3: Capital Stock Variation (in %) following a 1% increase in value added
Graph 4: Employment variation (in %) following a 1 % increase in actual cost
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This study lays the groundwork for a macro-sector modelling
of the Tunisian economy. It was delimited to the theoretical
specification of manufacturing industries and the econometric
estimation of the production block (demand for factors and price
of value added).
At the theoretical level, the various equations are based on the
principles used in computable general equilibrium models (CGEM),
while at the econometric level, estimates utilize the properties of
error-correction models (ECM).
Accordingly, the proposed model meets the requirements for the
internal consistency of long-term solutions and external coherence
with respect to observable data. The estimates conducted present
a certain number of outcomes worthy of interest:
- For most industries, the elasticities of substitution are close to
unity, which coincides with the traditional assumption of Cobb-
Douglas production functions. For some sectors, on the contrary,
(Textiles, Apparel, Leather and Various Industries), it is rather the
assumption of a production function with complementary factors
that seems to be appropriate.
- Overall, skilled and unskilled labour are revealed to be close
substitutes, thereby making the proportion of both types of input
very sensitive to changes in their relative cost.
- Dynamic simulations show that the Tunisian industrial sectors
are characterized by a relatively high rigidity in the adjustment
of factors: in the wake of demand or actual cost shocks, it
generally takes three to four years for a significant adjustment
to occur in the quantity of labour and capital.
Consequently, these preliminary findings make it possible to validate
both the theoretical assumptions and econometric methodologies
implemented. Hence, based on research work conducted under
this study, the estimation of sector prices and foreign trade - that
still have to be done - must be finalized in the relatively short run.
Conclusion
82
Bibliography
Annabi N., Cockburn J., Decaluwé B. (2003), Formes Fonctionnelles
et Paramétrisation dans les MCEG, CREFA, Université de
Laval.
Harrison R., Nikolov K., Quinn M., Ramsay G., Scott A. and
Thomas R. (2005), The Bank of England Quarterly Model,
www.bankofengland.co.uk/publications/beqm/
Klump R., McAdam P., Willman A. (2008), Unwrapping some euro
area growth puzzles: Factor substitution, productivity and
unemployment. Journal of Macroeconomics 30, 645–666
Lofgren H., Harris R.L., Robinson S. (2002), A standard computable
general equilibrium model in GAMS. Microcomputer in Policy
Research 5, International Food Policy Research Institute.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Chapter II
Modeling Tunisia’s Exports by Sector
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Table of Contents
85 Introduction
87 1. Presentation of Europe-Bround Sector Export Equations87 1.1 European Demand for Tunisia Imports: General Framework87 1.1.1 European Demand for Imports of Commodity87 1.1.2 Distribution of European Imports of Commodity88 1.1.3 Equation for Tunisian Exports of Commodity (i) to Europe88 1.2 Estimating the Equation for Tunisia Sector Exports: Error-Correction Model88 1.2.1 Error-Correction Model89 1.2.2 Estimation of dynamic Data Panel Models
90 2. Econometric Estimation of Tunisian Sector Export Equations90 2.1 Data91 2.2 Estimatio Method91 2.3 Key Outputs91 2.3.1 Agriculture94 2.3.2 IAA sector97 2.3.3 Building Materials, Ceramics and Glass Sector (MCCV)99 2.3.4 Mechinacal and Electrical Industries Sector101 2.3.5. Chemicals Sector104 2.3.6 Textile Apparel and Leather Sector106 2.3.7 Miscellaneous Sector «Miscel»108 2.3.8 Hydrocarbons and Refined Products Sector110 2.3.9 Total Goods112 2.3.10 Summary
114 3. Econometric Estimation of Tunisian Sector Export Equations in Dynamic Data Panel114 3.1 Data117 3.2 Estimation Method117 3.3 key Outputs117 3.3.1 ADL Model in Levels in tne Case of EU Prices (LPUE)118 3.3.2 ADL Model in Levels in the Case of Competitor Country Prices (LPCON)120 3.3.3 ADL Model in First Differences in the Case of EU Prices (DLPUE) 121 3.3.4 Error-Correction Model (ECM) in the Case of EU Prices (LPUE)123 3.3.5 Error-Correction Model (ECM) in the Case of Competitor Country Prices (LPCON)124 3.3.6 Error-Correction Model (ECM) in the case of Competitor Prices (LPCON)
127 4. Possible Extensions of Econometric Analysis127 4.1 A Foreign Trade Model ( in volume and in price)127 4.1.1 Volume Import Function127 4.1.2 Export Price Function128 4.1.3 Import Price Function128 4.2 VAR Modeling from the Cointegration Equation128 4.3 Non-linearities128 4.3.1 Income elasticity Variation Over time129 4.3.2 Price Elasticity Variation Over time130 4.4 Quantitative Rationing by Supply or by Demand
132 Conclusions133 Bibliography
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Introduction
This study sets out to analyse the determinants of Tunisian
exports, broken down into 8 sectors. Accordingly, it helps to
quantify the dynamics of sector exports as a result of variations
in expressed demand and relative prices.
This application will be delimited to the study of Tunisian exports
towards Europe, which represents the bulk of Tunisian exports,
based on annual data for the period 1988-2008.
The first section proposes a model of European import demand
for Tunisian commodities which, according to conventional
import functions17, leads to the introduction of 3 explanatory
variables:
- European expressed demand;
- Tunisian sector export price index;
- European price index; and
- Tunisia’s competitor price index on the European market.
Hence, this theoretical model is an extension of conventional
export models18 .
An econometric estimation methodology for this model is proposed
based on error-correction models. This technique helps to distinguish
between short-term elasticities and long-term elasticities of European
sector imports.
The second section presents the results obtained by the application
of this econometric methodology on Tunisian exports of goods,
broken down into eight sectors (plus total exports of goods). By
constraining the long-run elasticity of demand to a unit value, this
application is intended to reflect the changing market shares of
Tunisian exports to European countries.
Thereafter, the third section gives some estimates through dynamic
data panel methods.
Lastly, in the fourth section, some interesting modelling extensions
are discussed, which may be undertaken as a continuation of
previous work:
- First, estimated equations will be supplemented by a model
of sector prices and quantities (imports and exports), which
may help to determine nominal flows and trade balances
by sector;
- Second, some modelling and estimation avenues are proposed
for the purpose of introducing nonlinearities. These are intended
to take into account the possibility of time-varying elasticity. For
example, price elasticities may be lower when price differentials
are small and more significant when price differentials increase,
due to transaction costs; and
- Lastly, supply constraints will be integrated into the model. Indeed,
the previous modelling is limited to the specification and
17 See for example N. Annabi, Cockburn J., B. Decaluwé (2003) for an overview of the microeconomic foundations of the demand functions.18 See for example Wong (2008) for a recent application to the case of Malaysia.
86
estimation of European sector demand for Tunisian commodities.
However, especially in the presence of price rigidities, exports
may be limited by available supply and, consequently, actual
exports may not always correspond to European demand for
them. In this regard, a method has been proposed for the
estimation of a quantitative rationing model.
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87
1. Presentation of Europe-Bound Sector Export Equations
1.1 European Demand for Tunisian Imports:General Framework
1.1.1. European demand for imports of product (i)
The European demand function for the importation of commodity
(or sector) i is as follows:
(2) MiE = θΕ Yσ1 (PiE / Py)σ2
Where:
MiE: European import volume of commodity (i),
Y: European overall income volume
PiE: European import price index of commodity (i)
Py: European overall production price index
θΕ is a scale parameter
In principle, elasticities verify the following conditions:
Income elasticity: σ1 >0
European import price elasticity: σ2 <0
At the theoretical level, the following points may be underscored:
- In maximizing a utility function based on a CES function, income
asticity (σ1) is necessarily equal to1 (cf. Annabi et al., 2003).
- The price elasticity of demand for imports (σ2) is related to the
elasticity of substitution between European imports and domestic
production. If imports to Europe are perfect substitutes for local
production, price elasticity tends to minus infinity, whereas, if
they are complementary, price elasticity will tend towards
zero.
Additional remark:
- This equation may be used to analyse the imports of a European
country considered separately, rather than those of the entire
zone. In this case, Y and Py will respectively represent the income
and domestic price index of the European country considered.
- Other demand indicators such as consumption or investment
may be considered, rather than overall GDP (Y), if it is considered
that some commodities exported to Europe only meet consumer
demand (or alternatively investment demand). Consequently, the
consumer or investment price index should be retained as overall
price index, depending on the appropriate demand indicator.
1.1.2. Distribution of European imports of product (i)
The distribution of European imports may be written as follows:
(3) MiT = θΤ Mi
Eσ3 (PiT / PiE)σ4
In this case, MiT stands for European volume import of commodity
(i) from Tunisia (or Tunisian exports to Europe).
Similarly, PiT represents the European import price index for
commodity (i) from Tunisia.
Elasticities verify the following conditions:
- Elasticity of imports from Tunisia compared to total imports: σ3>0
- Price elasticity of imports from Tunisia with respect to total
European imports, for product (i): σ4<0
At the theoretical level, the price elasticity of imports from Tunisia
(σ4) reflects the elasticity of substitution between imports from Tunisia
and imports from other countries. If imports from Tunisia are perfect
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substitutes for imports from other countries, the price elasticity tends
to minus infinity, whereas, if they are complementary, the price
elasticity will tend towards zero.
1.1.3. Equation for Tunisian exports of product (i) to Europe
The two preceding equations express the European demand for
Tunisian commodities of sector (i):
(4) MiT = θΤ θΕ
σ3 Y σ3σ1 (PiE / Py ) σ3σ2 (PiT / PiE)σ4
This expression helps to show the:
- Income elasticity of imports of commodity (i) from Tunisia towards
Europe (σ3σ1>0)
- Price elasticity of imports of commodity (i) from Tunisia towards
Europe (σ4<0)
The estimation of the Equation for imports (i) from Tunisia to Europe
is realized by taking the logarithm of the above equation to obtain
a linear model:
(5) miT = χ0 y + β1 (piE - py) + β2 ( piT - piE ) + c
where:
miT = log(Mi
T) ; y = log(Y) ; py = log(Py) ; piE = log(PiE) ; piT = log(PiT)
χ0 = σ3σ1 ; β1 = σ3σ2 ; β2 = σ4 ; c= log(θΤ θΕσ3)
1.2 Estimating the Equation for Tunisian SectorExports: Error-Correction Model
1.2.1 Error-Correction Model
The econometric equation to be estimated will thus be as
follows:
(6) miT(t) = χ0 y(t) + β1 (piE(t) - py(t)) + β2 (piT(t) - piE(t)) + c + e(t)
where e(t) is the residual.
Hence, the estimated parameters of this equation will provide the
overall long-term elasticities compared to European income (χ0 > 0)
and with respect to Tunisian prices (a2<0).
Thus:
- a 1% increase in European income will be achieved in the long
run by an χ0% increase in Tunisian exports of commodity (i) to
Europe (ceteris paribus);
- a 1% increase in European prices will materialize in the long run
by a - β1% increase in Tunisian exports of commodity (i) to Europe
(ceteris paribus).
- a 1% increase in Tunisian prices will be achieved in the long run
by a - β2% decrease in Tunisian exports of commodity (i) to
Europe (ceteris paribus).
- a 1% increase in total European import prices will materialize in
the long run by a (β1 - β2)% variation in Tunisian export of
commodity (i) to Europe (ceteris paribus).
The estimation strategy of the model depends on the statistical
properties of the modelled series.
If one considers for example - which appears to be a reasonable
starting assumption to be confirmed by appropriate econometric
tests19 - that the variables of the model are I (1) using the terminology
of Engle and Granger (1987)20, i.e. if:
19 This involves implementing the usual unit root tests, e.g. Dickey and Fuller (1981).20 Intuitively, time series x(t) is integrated to order one (and noted I(1)) if it has a unit root, i.e. if it follows this process: x(t) = a.x(t-1) + b(L).Δx(t-1) + u(t) , where b(L) is a polynomialdelay, with a=1. Series x(t) will be I(0) if a<1.
89
miT(t) ~ I(1)
y(t) ~ I(1)
[piE(t) - py(t)] ~ I(1)
[piT(t) - piE(t)] ~ I(1)
the estimation of the model may be performed in two stages in
order to calculate long-term elasticities (by estimating the
cointegration relation 5) and short-term elasticities (by estimating
the error-correction model presented below).
The two-stage estimation is conducted as follows:
1. After verifying that the variables of interest are I(1), the following
cointegration relation (or long-term relation is estimated:
miT(t) = χ0 y(t) + β1 (piE(t) - py(t) ) + β2 ( piT(t) - piE(t) ) + c + ê(t)
2. The estimated residuals ê(t) are then tested and ascertained as
I(0) through the Engle and Granger (1981) cointegration tests.
3. If the previous stage validates the existence of a cointegration
relation, the error-correction model is then estimated as follows:
ΔmiT(t) = b1Δmi
T(t-1) + b2Δy(t) + b3 Δ[piE(t) - py(t)] + b4 Δ[piT(t) - piE(t)]
+ c0 + γ ê(t-1) + ε(t)
This expression helps to highlight the short-term value of income
elasticities (b2) and price elasticities (b3, b4), in addition to previously
estimated long-term elasticities.
The intuition behind this representation is as follows: Equation (5)
describes the "equilibrium" value of Tunisian imports, conditionally at
given income and relative prices. However, in the wake of a
shock affecting income or relative prices, Tunisian imports will not
immediately adjust but will converge more or less quickly towards
their new equilibrium. The adjustment speed towards the new
equilibrium is related to the value of parameter γ, (given that γ<0): if
γ is close to -1, the adjustment of imports towards the new equilibrium
will be long (thereby reflecting a strong inertia in imports relative to
European demand), whereas it will be faster if γ is close to 0.
The immediate effect of the shock affecting income or relative prices
is measured respectively by parameters b2, b3 and b4.
This representation may be used to simulate the expected exports
trajectories of Tunisia under different scenarios of change in relative
prices and income.
In conclusion, it is worth noting that if the two-stage approach helps
to intuitively present the distinction between short-term elasticities
and long-term elasticities, the one-stage estimation proposed by
Pesaran et al. (2001), supplemented by the critical values tabulated
for small samples by Narayan (2004), seems to be econometrically
more satisfactory and comprehensive than the two-stage approach
presented here.
1.2.2. Estimation of Dynamic Data Panel Models
Given that the stated objective is a sector-by-sector estimation of
price elasticities for Tunisian exports, the data panel estimation does
not seem to be relevant. However, if sector estimates turn out to be
disappointing (not robust or remote from theoretical a prioris), the
dynamic data panel estimation could be envisaged: either globally
or by a group of sectors with similar characteristics.
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2. Econometric Estimation of Tunisian Sector Export
Equations
The modelling proposed in the previous section suggests three
potential explanatory variables of Tunisian exports:
- European expressed demand;
- Tunisian sector export price index;
- European price index; and
- Tunisia's competitor price index on the European market.
However, preliminary estimates of export functions by sector have
revealed collinearity problems between different price indexes, which
made the estimated coefficients difficult to interpret. Therefore, the
following dynamic specification was retained, which is restricted to
the consideration of only one relative price (referenced p), which as
stated below, may take two different specifications:
(7) Δx(t) = ρΔx(t-1) + α0Δd(t) + α1Δd(t-1) + α2 Δd(t-2) + φ0Δp(t)
+ φ1Δp(t-1) + φ2Δp(t-2) + γ [ x(t-1) - βp(t-1) – d(t-1) + μ.t]
+ εt
Where:
x: logarithm of Tunisian exports to the European Union (EU) in
thousand Euros, constant 100= 2005 (compiled from comext).
d: logarithm of demand expressed to Tunisia by EU at constant
prices (compiled from comext). The expressed demand will be
presented in two alternative ways:
- The first considers demand expressed for all commodities in the
sector concerned (Agriculture, IAA,…);
- The second limits the demand to Tunisia's main exports in a
given sector (Agriculture, IAA,). Indeed, there is considerable
heterogeneity in the composition of commodities from each
sector, and in this form, expressed demand may be the more
representative model for Tunisian exports.
p: logarithm of the relative price of Tunisian exports. This relative
price is expressed in two alternative ways:
- The first one retains an index of sector relative prices for Tunisian
exports with respect to EU imports in the same sector;
- The second uses an index of relative prices for Tunisian exports
with respect to those of major competitors on the European market.
Hence, for each sector, 4 formulations were estimated according to
whether expressed demand should be calculated on all commodities or
restricted to the major export, and whether the relative price should be
calculated based on competitor prices or that of European Union countries.
It should be recalled that in this error-correction model (ECM), the term
in brackets [ x(t-1) - βp(t-1) – d(t-1)] represents the difference with respect
to long-term equilibrium wherein long-run elasticities are equal to 1 with
regard to expressed demand (in fact, Tunisia's market share trend is
modelled on the European market) and β in relation to relative price.
The term μ.t stands for the potential deterministic market share trend
which is growing annually at μ rate.
Lastly, the variables Δx represent the variation of x, and dummy
variables were sometimes included in the regression model.
2.1 Data
The estimation period spans from 1988 to 2008 in annual data. The
database was built within the ITCEQ team and comprises 8 sectors
91
as follows:
Sector 1: Agriculture (Agr)
Sector 2: Agri-food industry (IAA)
Sector 3: Ceramic Building Materials and Glass (MCCV)
Sector 4: Mechanical and Electrical Industries (IME)
Sector 5: Chemical Industries (CHEMI)
Sector 6: Textile, Apparel and Leather Industries (THC)
Sector 7: Miscellaneous Industries (MISCEL)
Sector 8: Hydrocarbons (Hyd).
2.2 Estimation Method
The method of estimation selected here is an Error-Correction Model
(ECM) estimated in one stage, following the approach proposed by
Pesaran et al. (2001). It involves estimating an unconstrained form
of equation (6):
Δx(t) = ρΔx(t-1) + α0Δd(t) + α1Δd(t-1) + α2 Δd(t-2) + φ0Δp(t) +
φ1Δp(t-1) + φ2Δp(t-2) + a.x(t-1) + b.p(t-1) + c.d(t-1) + εt
and to test the significance of parameter (a): if it is significantly different
from zero, it is concluded that there is an error-correction mechanism
and the long-term coefficients can easily be determined from
estimated parameters a, b and c.
Before proceeding with the econometric estimation, the order of
integration of the series used was tested using the ADF test. The
results show that the entire series tested are all integrated to order 1.
2.3 Key Outputs
2.3.1. Agriculture
The key outputs, for the 4 specifications tested for this sector, are
summarized in Table 1:
• The value of the long-run elasticity of demand for exports was
imposed to unity. It is worth noting that, in preliminary tests, this
restriction is more easily accepted by using expressed demand
calculated on the basis of major products;
• Whenever expressed demand for "Total commodities " is used,
our estimates reveal a significantly positive trend, representing
an increase in market share trend for this sector;
• Long-term price elasticities bear the expected sign in 3 out of 4
cases. Only the formulation with EU prices and "major
commodities" for demand bears a positive sign, contrary to
economic intuition. The value of this elasticity is low, to the tune
of -.2 in the case of competitor prices and -0.3 in that of EU
countries, which would imply that Tunisian products in the sector
have few substitutes on the EU import market; and
• ECMs that use "Total commodities" for demand have satisfactory
statistical properties. LM tests result in the rejection of the hypothesis
of autocorrelation in the residuals of these equations. These residuals
are homoskedastic under the White test and the ARCH test. The
functional form of the equation passed the Reset test. Lastly,
according to the Jarque Bera test, the residuals of all equations
are normally distributed. That is not the case for those using "Major
commodities " for demand.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
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At the end of these estimates, it seems the best equation is the one
that uses "Total exports" as expressed demand and considers the
prices of EU countries as foreign price.
Graph 1 illustrates the static adjustment of this ECM in the past.
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy (-3.70) (-1.45) (-2.21) (-3.28) γ
Relative prices of …
… competitors -0.20 (-0.28) -0.17 (-1.00) β
… EU as a whole -0.30 (-2.09) 0.06 (0.12)
Trend 0.007 (2.12) 0.02 (1.81) 2.0 2.0 μ
ST Elasticities
Δlog(expressed demand) 1.49 (3.57) α0
Dummy
d98 0.16** (1.91) 0.16* (2.03) η0
d06 0.23 (2.32) η1
d02 -0.14 (-1.72) η2
Tests
LM (2) 0.82 0.21 0.03 0.10
Arch(1) 0.72 0.33 0.72 0.33
Normality 0.71 0.56 0.92 0.38
Reset (2) 0.97 0.29 0.08 0.05
R-squared 0.63 0.50 0.44 0.39
Adjusted R-squared 0.46 0.32 0.34 0.33
Ranking 1 4 3 2
Source: ITCEQ/DEFI CalculationsNote: Student's t-statistic is shown in brackets ne: coefficient was not estimated but imposed.
Table 1: Summary of Key Findings of the Export Equation Estimates for Sector 1 (Estimation Period 1988-2008)
93
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Graph 1: Annual Growth rate of Tunisian Exports in Sector 1 observed and adjusted
Source : ITCEQ/DEFI Calculations
Graph 2 represents the response of Agriculture sector exports in
the wake of 2 simulated shocks, by retaining the best specification
from Table 1 (column 1):
- A 1% increase in expressed demand;
- A 1% increase in the relative price of Tunisian exports.
This graph shows that the median adjustment period21 is slightly
above one year in the case of a price shock, whereas in the case
of a demand shock, there currently is a phenomenon of short-term
"overshooting" versus long-term equilibrium (elasticity of demand
stands at 1.49 in the short run and at 1 in the long term.
These results imply that following a decline in demand for imports
in the EU21, Tunisian agricultural exports may be substantially
affected (about a 1.5% decline, with respect to the trend
throughout the year, in Tunisian exports in case of a 1% drop in
European demand), which would make it one of the sectors most
affected by the European economic downturn. Furthermore, the
consequence of the low price elasticity is that a fall in Tunisian
prices would not be able to significantly offset the decrease in
exports during a recession in Europe.
21 C’est-à-dire le nombre d’années nécessaires pour que la moitié de l’ajustement total soit réalisé.
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A 1% increase in expressed demand A 1% increase in the relative price of Tunisian exports
Graph 2 : Responses to shocks
Source : Calculs ITCEQ/DEFI
2.3.2. IAA Sector
The key outputs for this sector are summarized in Table 2:
• The value of elasticity of demand for exports was imposed to
unity. It is worth noting that this restriction is accepted in all cases;
• Long-term price elasticities have the expected sign in three out
of four cases. Only the formulation with the price of EU countries
and "major commodities " for demand bears a positive sign,
contrary to economic intuition. The value of this elasticity is -0.7
in the case of competitor prices and -0.5 in that of EU countries;
and
• All ECMs have satisfactory statistical properties. LM tests
result in the rejection of the hypothesis of autocorrelation in
the residuals of these equations. These residuals are
homoskedastic under the White test and the ARCH test. The
functional form of the equation passed the Reset test. Lastly,
according to the Jarque Bera test, the residuals of all equations
are normally distributed.
According to these estimates, the best equation is the one that uses
"Total commodities" for demand and considers the prices of EU
countries as foreign price. Findings are summarized in the table
below.
95
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy -1.13 (-6.10) -1.19 (-5.82)) -1.19 (-9.94) -1.33 (-5.99) γ
Relative prices of …
… competitors -0.64 (-1.87) -0.74 (-2.39) β
… EU as a whole -0.54 (-1.61) 0.26 (2.47)
Trend μ
ST Elasticities
Δlog(expressed demand) -0.89 (-2.61) -0.93 (-2.54) -0.75* (-2.06) α0
Dummy
d02 -0.93 (-3.52) -0.87 (-3.25) -0.98 (-3.97) -1.12 (-4.11) η0
d01 -0.96 (-3.10) -0.90 (-2.74) -0.93 (-3.13) -1.15 (-3.32) η1
d96 -0.14 (-1.72) -0.79 (-3.32) η2
d94 0.48* (2.09) 0.62 (3.74) η3
Tests
LM (2) 0.55 0.32 0.37 0.87
Arch(1) 0.85 0.70 0.33 0.93
Normality 0.80 0.86 0.83 0.74
Reset (2) 0.10 0.52 0.12 0.76
R-squared 0.87 0.81 0.86 0.82
Adjusted R-squared 0.80 0.75 0.80 0.76
Ranking 1 3 4 2
Table 2: Summary of Key Findings of the Export Equation Estimates for Sector 2 (Estimation Period 1988-2008)
Source: ITCEQ/DEFI CalculationsNote: Student's t-statistic is shown in brackets ne: coefficient was not estimated but imposed.
Graph 3 illustrates the static adjustment of this ECM in the past.
96
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Graph 3: Annual Growth rate of Tunisian Exports in Sector 2 observed and adjusted
Source : ITCEQ/DEFI Calculations
Graph 4 represents the response of IAA sector exports in the wake
of a 1 % shock on demand and relative price, by retaining the best
specification from Table 2 (column 1).
The median adjustment period is very short, i.e. less than one year,
in the case of a demand shock, whereas, in the case of a price shock,
there is short-term overshooting with respect to long-term equilibrium
(price elasticity stands at -0.89 in the short run and at -0.54 in the
long term). Hence, a recession in Europe would have very swift and
egregious adverse impacts on Tunisian IAA sector exports. However,
a fall in export prices would be able to, at least partly offset such an
impact.
Source : ITCEQ/DEFI Calculations
A 1% increase in expressed demand A 1% increase in the relative price of Tunisian exports
Graph 4: Responses to Shocks
97
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2.3.3. Ceramic Building Materials and Glass Sector (MCCV)
The key outputs for this sector are summarized in Table 3:
• The value of elasticity of exports demand was imposed to unity.
It is worth noting that this restriction is accepted econometrically
in the case of "Total commodities ". The elasticity in the case of
"Major commodities " is close to 0.6 when the coefficient is
left free.
• Long-term price elasticities bear the expected sign in all cases.
The value of this elasticity is close to -0.5.
• ECMs that use "Total commodities " for demand have
satisfactory statistical properties. LM tests result in the rejection
of the hypothesis of autocorrelation in the residuals of
these equations. These residuals are homoskedastic under
the White test and the ARCH test. The functional form of the
equation passed the Reset test. Lastly, according to the Jarque
Bera test, the residuals of all equations are normally distributed.
That is not the case for those using "Major commodities " for
demand.
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy -0.88 (-6.66) -0.87 (-6.63) -0.74 (-4.70) -0.73 (-4.92)γ
Relative prices of …
… competitors -0.46 (-3.81) -0.57 (-3.21)β
… EU as a whole -0.44 (-3.64) -0.49 (-2.69)
Trend μ
ST Elasticities
Dummy
d9293 -0.52 (-2.86) -0.51 (-2.84) -0.68 (-2.78) -0.63 (-2.76)η0
Tests
LM (2) 0.52 0.70 0.49 0.61
Arch(1) 0.35 0.41 0.58 0.75
Normality 0.63 0.68 0.26 0.23
Reset (2) 0.37 0.23 0.01 0.01
R-squared 0.85 0.86 0.76 0.79
Adjusted R-squared 0.83 0.83 0.72 0.75
Ranking 1bis 1 3bis 3
Table 3: Summary of Key Findings of the Export Equation Estimates for Sector 3 (Estimation Period 1988-2008)
Source: ITCEQ/DEFI CalculationsNote: Student's t-statistic is shown in brackets ne: coefficient was not estimated but imposed.
The best equation is one that uses "Total exports" as expressed
demand. (1st column). The distinction on prices does not seem to
be differentiating in this sector.
Graph 5 illustrates the static adjustment on the past of this ECM.
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In the graph for responses to shocks (Graph 6 based on Table 3,
column 1), the median period is short, about a year, for both types
of shocks: a 1% fall in European demand should result in about a
0.5% decrease in IMCCV sector exports over one year.
Source: ITCEQ/DEFI Calculations
Graph 5: Annual Growth Rate of Tunisian Exports in Sector 3 observed and adjusted
Source: ITCEQ/DEFI Calculations
A 1% increase in expressed demand A 1% increase in the relative price of Tunisian exports
Graph 6 : Responses to Shocks
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2.3.4. Mechanical and Electrical Industries Sector
The key outputs for this sector are summarized in Table 4:
• The value of elasticity of demand for exports was imposed to
unity. Unstressed, such elasticity would exceed unity, reaching
around 1.3 in both cases;
• In all ECMs, estimates reveal a significantly positive trend,
signifying an increased market share trend in this sector. This is
consistent with elasticity of expressed demand exceeding unity;
• Long-term price elasticities do not have the expected sign when
competitor prices are included in the relative price. In the other
case, the estimated elasticity is relatively high, between -1 and
-1.5; and
• All ECMs have satisfactory statistical properties. LM tests
result in the rejection of the hypothesis of autocorrelation in
the residuals of these equations. These residuals are
homoskedastic under the White test and the ARCH test. The
functional form of the equation passed the Reset test. Lastly,
according to the Jarque Bera test, the residuals of all equations
are normally distributed.
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy -0.22 (-2.31) -0.13 (-2.27) -0.66 (-8.86) -0.73 (-2.71) γ
Relative prices of …
… competitors 0.09 0.27 β
… EU as a whole -1.10 -1.56
Trend 0.09 0.08 0.10 0.06 μ
ST Elasticities
Δlog(expressed demand) 0.42 (4.36) 0.35 (2.92) 0.72 (8.91) α0
Δ(Relative prices) -0.32 (-2.77) -0.14 (-1.24) -0.53 (-6.24) α0
Δ(Relative prices) -1 0.39 (4.12) α1
Δlog(Exports)-2 -0.28 (-4.91) ρ0
Dummy
d89 0.14 (3.60) 0.12 (2.48) η0
d06 0.16 (3.28) 0.17 (2.70) 0.10 (7.65) η1
d96 -0.18 (-3.68) η2
Tests
LM (2) 0.34 0.54 0.36 0.51
Arch(1) 0.72 0.86 0.16 0.32
Normality 0.67 0.34 0.72 0.35
Reset (2) 0.64 0.40 0.83 0.35
R-squared 0.83 0.75 0.98 0.63
Adjusted R-squared 0.73 0.61 0.96 0.53
Ranking 1bis 3 1 3bis
Table 4: Summary of Key Findings of the Export Equation Estimates for Sector 4 (Estimation Period: 1988-2008)
Source: ITCEQ/DEFI CalculationsNote: Student's t-statistic is shown in brackets ne: coefficient was not estimated but imposed.
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The best equation is one that uses prices calculated on all EU countries
in the competitiveness indicator, and for major exports only.
Graph 7 illustrates the static adjustment on the past of this ECM.
Source: ITCEQ/DEFI Calculations
Graph 7: Annual Growth Rate of Tunisian Exports in Sector 3 observed and adjusted
The response to simulated shocks is shown in Graph 8 by retaining
the best specification from Table 4 (column 3). For the demand shock,
the median period is instantaneous (given that short-term elasticity is
greater than 0.5 for a long-term elasticity equal to 1), and it is less
than one year for the relative price shock. The effects of a European
recession here are similar to those of IMCCV sector: a 1% drop in
European demand should lead to a rapid decrease of about 0.5% (in
deviation from trend) in IME sector exports. However, the sensitivity
of these exports to relative prices implies that a reduction in prices
would be able to partially offset this movement.
101
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Graph 8: Responses to Shocks
Source : ITCEQ/DEFI Calculations
2.3.5. Chemical Sector
The key outputs for this sector are summarized in Table 5:
• The value of elasticity of demand for exports was imposed to
unity. Unstressed, such elasticity would exceed unity, reaching
around 1.5 in all cases, except for case 4 (expressed demand,
“major commodities”, competitor prices), where elasticity stands
at 0.8;
• In all ECMs, estimates reveal a significantly negative trend,
signifying a loss-of-market share trend in this sector. This is
consistent with elasticity of demand below unity;
• Price elasticities bear the expected sign, regardless of the
formulation used, although their value varies greatly: it stands
around -0.7 / -0.9 in the case of a "Total commodities" demand.
These values become much higher (-1.89 and -4.67 respectively)
when expressed demand includes "Major commodities". This
indicates a high degree of substitutability of Tunisia's chemical
exports with respect to competing exports; and
• All ECMs have satisfactory statistical properties. LM tests
result in the rejection of the hypothesis of autocorrelation
in the residuals of these equations. These residuals are
homoskedastic under the White test and the ARCH test. Lastly,
according to the Jarque Bera test, the residuals of all equations
are normally distributed. The functional form of the equation
alone failed the Reset test.
102
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy -0.75 (-2.70) -0.67 (-2.36) -0.23 (-1.99) -0.39 (-3.55) γ
Relative prices of …
… competitors -0.88 (-2.35) -4.67 (-3.91) β
… EU as a whole -0.70 (-2.69) -1.89 (-2.09)
Trend -0.06 (-3.40) -0.06 (-3.19) -0.11 (-2.63) -0.13 (-4.47) μ
ST Elasticities
Δlog(expressed demand) 0.87 * (2.01) 0.72 ** (1.65) α0
Δ(Relative prices) -0.32 (-2.77) -0.14 (-1.24) -0.15 ** (-1.79) α0
Δ(Relative prices) -1 1.52 (2.90) φ1
Δlog(Exports)-2 1.39 (3.00) φ2
Dummy
d9394 -0.18* (-2.26) -0.19 * (-2.28) -0.24 (-2.69) -0.28 (-4.08) η0
Tests
LM (2) 0.75 0.42 0.73 0.19
Arch(1) 0.49 0.91 0.37 0.30
Normality 0.63 0.68 0.61 0.42
Reset (2) 0.07 0.10 0.07 0.02
R-squared 0.74 0.73 0.65 0.86
Adjusted R-squared 0.62 0.60 0.53 0.74
Ranking 2 3 4 1
Table 5: Summary of Key Findings of the Export Equation Estimates for Sector 5 (Estimation Period: 1988-2008)
Source: ITCEQ/DEFI CalculationsNote: Student's t-statistic is shown in brackets ne: coefficient was not estimated but imposed.
At the end of these estimates, it seems the best equation is one that
uses prices calculated based on competitor prices in thecompetitiveness
indicator and considers expressed demand as "Total commodities".
Graph 9 illustrates the static adjustment on the past of this ECM.
103
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Source : ITCEQ/DEFI Calculations
Graph 9: Annual Growth Rate of Tunisian Exports in Sector 5 observed and adjusted
Source : Calculs ITCEQ/DEFI
A 1% increase in expressed demand A 1% increase in the relative price of Tunisian exports
Chemical sectorChemical sector
Graph 10: Responses to Shocks
The median adjustment period for chemical industry exports seems
to be long (Graph 10): to the tune of 2 years for demand shock and 4
years for relative price shock. In the scenario of a European recession,
exports should not be excessively reduced (in deviation from trend)
over a period of one year, whereas high price elasticity helps to consider
relative price adjustments capable of offsetting such reduction.
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2.3.6. Textile, Apparel and Leather Sector
The key outputs for this sector are summarized in Table 6:
• The value of elasticity of demand for exports was imposed to
unity. Such unstressed elasticity would fall below unity, and stand
at about 0.6 in all cases;
• Price elasticities bear the expected sign, regardless of the
formulation used, and their value is high, standing between -3
and -4 when competitor prices are used and between -5 and -
8 in the other case. Consequently, as in the case of chemical
industries, there would be a phenomenon of high substitutability
of these exports on the European market; and
• All ECMs have satisfactory statistical properties. LM tests
result in the rejection of the hypothesis of autocorrelation
in the residuals of these equations. These residuals are
homoskedastic under the White test and the ARCH test. The
functional form of the equation passed the Reset test. Lastly,
according to the Jarque Bera test, the residuals of all equations
are normally distributed.
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy -0.14 (-2.12) -0.15 (-3.31) -0.10 (-2.21) -0.15 (-3.56) γ
Relative prices of …
… competitors 2.88 (-9.01) -4.21 (-8.27) β
… EU as a whole -5.30 (-4.99) -8.04 (-6.39)
Trend μ
ST Elasticities
Δ(Relative prices) -0.26 (-2.33) -0.34 (-3.10) -0.43 (-3.63) -0.46 (-3.94) φ0
Dummy
d9394 0.16 (2.41) 0.15 (2.25) 0.19 (2.73) η0
Tests
LM (2) 0.84 0.48 0.62 0.46
Arch(1) 0.36 0.69 0.62 0.88
Normality 0.69 0.98 0.64 0.58
Reset (2) 0.16 0.89 0.77 0.77
R-squared 0.65 0.84 0.80 0.86
Adjusted R-squared 0.55 0.81 0.76 0.82
Ranking 4 2 3 1
Table 6: Summary of Key Findings of the Export Equation Estimates for Sector 6 (Estimation Period: 1988-2008)
Source: ITCEQ/DEFI CalculationsNote: Student's t-statistic is shown in brackets ne: coefficient was not estimated but imposed.
105
At the end of this initial study, it would seem the best equation is
one that uses prices calculated based on competitor prices in the
competitiveness indicator and considers expressed demand as
"Total commodities".
Graph 11 illustrates the static adjustment on the past of this
ECM.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
The estimated median adjustment periods for Textiles, Apparel
and Leather industry exports are the longest among the sectors
studied (Figure 12): they are close to 5 years for the demand shock
and over 3 years for the relative price shock. In the short term, a
European recession should not have much effect on those exports.
As in the case of the chemical industry, significant price elasticity
helps to consider relative price adjustments capable of offsetting
a possible decline in exports.
Source: ITCEQ/DEFI Calculations
Graph 11: Annual Growth Rate of Tunisian Exports in Sector 6 observed and adjusted
Source: ITCEQ/DEFI Calculations
A 1% increase in expressed demand A 1% increase in the relative price of Tunisian exports
Textile, Apparel and LeatherTextile, Apparel and LeatherGraph 12: Responses to Shocks
106
2.3.7. Miscellaneous Sector
The key outputs for this sector are summarized in Table 7:
• The value of elasticity of demand addressed for exports was
imposed to unity. It is worth noting that this restriction is accepted
more easily by using expressed demand calculated on the basis
of major exports (estimated elasticity of 1.05) than for "Total
commodities" (estimated elasticity greater than 1.7).
• Price elasticities never have the expected sign except for
case 3 (expressed demand for "Major commodities" and
prices of EU countries. In the latter case, the estimated value
is -1.5.
• All ECMs have satisfactory statistical properties. LM tests
result in the rejection of the hypothesis of autocorrelation in
the residuals of these equations. These residuals are
homoskedastic under the White test and the ARCH test. The
functional form of the equation passed the Reset test. Lastly,
according to the Jarque Bera test, the residuals of all
equations are normally distributed.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy -0.12 (-2.59) -0.31 (-2.96) -0.38 (-4.62) -0.12 (-2.18)γ
Relative prices of …
… competitors 0.07 (0.30) 0.41 (0.69) β
… EU as a whole 2.52 (2.71)-1.43 (-3.74)
Trend 0.08 (2.57)0.05 (3.74)
0.07 (1.46) μ
ST Elasticities
Δ(Relative prices) 0.09 ** (1.49)
α0
Δlog(Expressed demand)-10.16 (3.00)
α1
Dummy
d98 0.18 (2.42)0.18 (2.14) η0
d02 0.19 * (2.00)0.19 (2.22)
0.20 (2.66)η1
Tests
LM (2) 0.37 0.60 0.74 0.36
Arch(1) 0.74 0.75 0.78 0.82
Normality 0.90 0.08 0.63 0.03
Reset (2) 0.65 0.96 0.64 0.95
R-squared 0.43 0.60 0.71 0.66
Adjusted R-squared 0.32 0.46 0.58 0.47
Ranking 4 3 1 2
Table 7: Summary of Key Findings of the Export Equation Estimates for Sector 7 (Estimation Period: 1988-2008)
Source: ITCEQ/DEFI CalculationsNote: Student's t-statistic is shown in brackets ne: coefficient was not estimated but imposed.
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The best equation is one that uses prices calculated based on
competitor prices in the competitiveness indicator and considers
expressed demand as "Total commodities".
Graph 13 illustrates the static adjustment on the past of this ECM.
Source: ITCEQ/DEFI Calculations
Graph 13: Annual Growth Rate of Tunisian Exports in Sector 7 observed and adjusted
Source: ITCEQ/DEFI Calculations
A 1% increase in expressed demand A 1% increase in the relative price of Tunisian exports
Miscellaneous SectorMiscellaneous SectorGraph 14: Responses to Shocks
The estimated responses to shocks for this sector (Graph 14)
reveal very short median adjustment periods (about 1 year) following
a demand shock, and to the tune of 2 years in the wake of a price
shock. Hence, a 1% fall in European demand would be attended
by a 0.5% drop in sector exports within 1 year (in deviation
from trend).
108
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2.3.8. Hydrocarbons and Refined Products Sector
The key outputs for this sector are summarized in Table 8:
• The value of elasticity of demand for exports was imposed to
unity. It is worth noting that this restriction is more easily accepted
when using expressed demand calculated on the basis of “Total
commodities” (estimated elasticity is 1.03) than in the case of
“Major commodities” (elasticity estimated above 0.8);
• Price elasticities always have the expected sign. The value ranges
between -8 in the case of EU prices and around -5 in the case
of competitor prices. This sector is characterized by the highest
price elasticities among the sectors studied. This is not surprising,
given the type of products involved in the sector: hydrocarbons
are standardized exports, and Tunisian products are close
substitutes with respect to exports traded on the European
market; and
• All ECMs have satisfactory statistical properties. LM tests result
in the rejection of the hypothesis of autocorrelation in the residuals
of these equations. These residuals are homoskedastic under
the White test and the ARCH test. The functional form of the
equation passed the Reset test. Lastly, according to the Jarque
Bera test, the residuals of all equations are normally distributed.
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy -0.83 (-6.31) -0.41 (-2.31) -0.66 (-3.75) -0.38 (-2.02)γ
Relative prices of …
… competitors -5.65 (-1.69) -4.47 (-1.29)β
… EU as a whole -7.93-7.93 (-3.81)
Trend μ
ST Elasticities
Dummy
d9394 -0.53 (-4.52) -0.68 (-3.60) -0.65 (-5.09) -0.71 (-3.74)η0
Tests
LM (2) 0.11 0.26 0.65 0.30
Arch(1) 0.83 0.84 0.12 0.84
Normality 0.89 0.27 0.73 0.21
Reset (2) 0.80 0.68 0.30 0.62
R-squared 0.89 0.69 0.86 0.67
Adjusted R-squared 0.87 0.63 0.82 0.61
Ranking 1 3 2 4
Table 8: Summary of Key Findings of the Export Equation Estimates for Sector 8 (Estimation Period: 1988-2008)
Source: ITCEQ/DEFI CalculationsNote: Student's t-statistic is shown in brackets ne: coefficient was not estimated but imposed.
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At the end of this initial work, it seems the best equation is one that
uses "Total commodities" as expressed demand and considers the
prices of EU countries as foreign price.
Graph 15 illustrates the static adjustment on the past of this ECM.
Source: ITCEQ/DEFI Calculations
Graph 15: Annual Growth Rate of Tunisian Exports in Sector 8 observed and adjusted
Source: ITCEQ/DEFI Calculations
A 1% increase in expressed demand A 1% increase in the relative price of Tunisian exports
hydrocarbon and Refined Products Sectorhydrocarbon and Refined Products SectorGraph 16: Responses to Shocks
As might be expected, median adjustment periods are very
short: less than one year following demand shocks or price
shocks. The notable fact here is that high price elasticity
and short adjustment periods jointly make exports from this
sector very sensitive to short-term fluctuations in relative
prices.
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2.3.9. Total Goods
The key outputs for this sector are summarized in Table 9:
• The value of elasticity of demand for exports was imposed to
unity. It is worth noting that this restriction is more easily accepted
when using expressed demand calculated on the basis of “Total
commodities” (estimated elasticity is 1.01) than in the case of
“Major commodities” (elasticity estimated above 0.9);
• Price elasticities always have the expected sign except for
formulation 3 (prices of all EU countries and expressed demand
as “Major commodities”). In the other cases, the value stands
between -0.3 and -0.5; and
• All ECMs have satisfactory statistical properties. LM tests
result in the rejection of the hypothesis of autocorrelation in
the residuals of these equations. These residuals are
homoskedastic under the White test and the ARCH test. The
functional form of the equation passed the Reset test.
Lastly,Bera test, the residuals of all equations are normally
distributed.
Total Commodities Major Commodities
LT Elasticities
Expressed demand 1ne 1ne 1ne 1ne
Buoyancy -0.53 (-5.14) -0.49 (-4.28) -0.53 (-3.93) -0.57 (-5.59) γ
Relative prices of …
… competitors -0.49 (-3.30) -0.31 (-2.40) β
… EU as a whole -0.53 (-2.18) 0.35 (1.05)
ST Elasticities
Δlog(Expressed demand)-1 -0.44 (-2.65) α1
Δ(Relative prices)-1 -0.35 (-1.95) φ1
Dummy
d9394 -0.14 (-4.89) -0.11 (-5.07) -0.13 (-4.75) -0.12 (-4.94) η0
Tests
LM (2) 0.59 0.36 0.78 0.87
Arch(1) 0.55 0.86 0.51 0.43
Normality 0.73 0.96 0.20 0.42
Reset (2) 0.08 0.17 0.14 0.87
R-squared 0.78 0.83 0.75 0.82
Adjusted R-squared 0.74 0.78 0.68 0.79
Ranking 3 2 4 1
Table 9: Summary of Key Findings of the Export Equation Estimates for Sector 9 (Estimation Period: 1988-2008)
Source: ITCEQ/DEFI CalculationsNote: Student's t-statistic is shown in brackets ne: coefficient was not estimated but imposed.
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Source: ITCEQ/DEFI Calculations
Graph 17: Annual growth rate of Tunisian exports to Total Assets observed and adjusted
The best equation is one that uses "Total commodities" as expressed
demand and considers competitor prices as foreign price.
Graph 17 illustrates the static adjustment on the past of this
ECM.
Graph 18 is used to summarize the dynamic effects that could
be expected from a 1% decline in European demand for the
volume of Tunisian exports. Given that these are mainly performed
in the Textiles, Apparel and Leather sector (approximately 40%
of total exports of goods in 2008 in the sector coverage of the
database used) and Mechanical and Electrical Industries (about
30% of total exports of goods in 2008, the same sources),
responses to shocks are closely linked to the dynamic behaviour
of both sectors.
Regarding the demand shock, the median adjustment period is
about one year: a 1% drop in European demand would therefore
materialize by reducing the volume of goods exported by about
0.5% over one year.
Long-term price elasticity is relatively low (-0.31) and the median
period of adjustment to a price shock is significantly greater than
one year: overall, a limited variation in relative prices should have
little impact on the quantities exported over one year.
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Source : ITCEQ/DEFI Calculations
Total AssetsTotal Assets A 1% increase in expressed demand A 1% increase in the relative price of Tunisian exports
Graph 18: Responses to Shocks
2.3.10. Summary
Table 10 summarizes the ranking of formulations by sector. It seems
that formulation 1 (expressed demand as "total commodities" and
prices of all EU countries as foreign prices) appears as the most
acceptable if a formulation common to all sectors should be retained.
Relative prices of… Total Commodities Major Commodities
Sector 1… competitors 4 2
… EU as a whole 1 3
Sector 2… competitors 3 2
… EU as a whole 1 4
Sector 3… competitors 1
… EU as a whole 1 bis 3 bis
Sector 4… competitors 3 4
… EU as a whole 1 bis 1
Sector 5… competitors 3 1
… EU as a whole 2 4
Sector 6… competitors 2 1
… EU as a whole 4 3
Sector 7… competitors 3 2
… EU as a whole 4 1
Sector 8… competitors 3 4
… EU as a whole 1 2
Total Goods… competitors 2 1
… EU as a whole 3 4
Table 10: Summary of Best Sector Specification
Source: ITCEQ/DEFI Calculations
113
In conclusion, the findings of the estimates conducted provide
important lessons, as they highlight huge differences among sectors,
both with respect to the long-term price elasticities of the various
sectors (and hence their level of substitutability on the European
market), and to the dynamic behaviour of Tunisian exports in the
wake of relative price shocks and demand shocks.
It should be emphasized that responses to shocks were discussed
with the example of a European recession (and a decrease in import
demand from the EU). However this does not, in any way, involve
short-term economic forecasting: indeed, while it is true that
European imports plummeted (to the tune of 40% in value and in
monthly data) from their peak in July 2008 to record lows in
September 2009, it should be acknowledged also that they have,
since that date, recorded very strong growth and are almost back
to their pre-crisis level since January 2011.
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3. Econometric Estimates of Tunisia's Sector Export
Equations through Dynamic Panel Analysis
Export functions were estimated through dynamic panel
analysis.
3.1 Data
The estimation period spans from 1988 to 2008. The database was
built with the ITCEQ team and comprises 8 sectors presented in the
previous section:
Sector 1: Textile, Apparel and Leather Industries (THC)
Sector 2: Mechanical and Electrical Industries (IME)
Sector 3: Agri-food Industry (IAA)
Sector 4: Ceramic Building Materials and Glass Industry (IMCCV)
Sector 5: Miscellaneous Industries (MISCEL)
Sector 6: Chemical Industries (CHEMI)
Sector 7: Agriculture (AGRICULTURE)
Sector 8: Hydrocarbons (HYDRPDSRAFFINES)
Panel data variables are as follows:
X: Tunisian exports, the logarithm will be denoted by LX and the
logarithm variation will be denoted by DLX;
D: European demand, the logarithm will be denoted by LD and the
logarithm variation will be denoted by DLD;
PCON: Relative price of Tunisian exports with respect to competitor
prices, the logarithm will be denoted by LPCON and the logarithm
variation will be denoted by DLPCON;
PUE: Relative price of Tunisian exports with respect to European
Union prices, the logarithm will be denoted by LPUE and the logarithm
variation will be denoted by DLPUE
The modelled variables will be expressed in logarithms and before
proceeding with the econometric estimation proper, the order of
integration of the series used was tested with the panel unit root
tests.
Table 11: Findings of Panel Unit Root Tests
Panel unit root test: Summary Sample: 1988 2008
Exogenous variables: Individual effects, individual linear trends
Automatic selection of maximum lags based on SIC: 0 to 3
Newey-West automatic bandwidth selection and Bartlett kernel
Tunisian Exports (LX)
Method Statistic Prob.** Cross-sections Obs
Null: Unit root (assumes common unit root process)
Levin, Lin & Chu t* -1.58336 0.0567 8 156
Breitung t-stat 3.92219 1.0000 8 148
Null: Unit root (assumes individual unit root process)
Im, Pesaran and Shin W-stat -1.94229 0.0261 8 156
ADF - Fisher Chi-square 31.8442 0.0105 8 156
PP - Fisher Chi-square 42.1884 0.0004 8 160
115
The findings of unit-root tests differ from one another and indicate
that the series may be stationary or integrated to order 1.
In the case the series are assumed to be integrated to order 1.
Pedroni's Cointegration tests (Table 12) also give conflicting results
(the null hypothesis of noncointegration may be rejected or not
rejected by the test applied).
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Demand (LD)
Method Statistic Prob.** Cross-sections Obs
Null: Unit root (assumes common unit root process)
Levin, Lin & Chu t* -1.46385 0.0716 8 152
Breitung t-stat -0.29669 0.3834 8 144
Null: Unit root (assumes individual unit root process)
Im, Pesaran and Shin W-stat -2.12314 0.0169 8 152
ADF - Fisher Chi-square 30.3855 0.0161 8 152
PP - Fisher Chi-square 30.6235 0.0150 8 160
Relative prices calculated based on competitor prices (LPCON)
Method Statistic Prob.** Cross-sections Obs
Null: Unit root (assumes common unit root process)
Levin, Lin & Chu t* -2.09402 0.0181 8 155
Breitung t-stat 0.84405 0.8007 8 147
Null: Unit root (assumes individual unit root process)
Im, Pesaran and Shin W-stat -2.60662 0.0046 8 155
ADF - Fisher Chi-square 35.3177 0.0036 8 155
PP - Fisher Chi-square 27.4481 0.0368 8 160
Relative prices calculated based on European Union prices (LPUE)
Method Statistic Prob.** Cross-sections Obs
Null: Unit root (assumes common unit root process)
Levin, Lin & Chu t* -3.55244 0.0002 8 151
Breitung t-stat 1.31856 0.9063 8 143
Null: Unit root (assumes individual unit root process)
Im, Pesaran and Shin W-stat -3.04380 0.0012 8 151
ADF - Fisher Chi-square 38.7938 0.0012 8 151
PP - Fisher Chi-square 16.8827 0.3932 8 160
** Probabilities for Fisher tests are computed using an asymptotic Chi -square distribution. All other tests assume asymptotic normality.
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Table 12: Findings of panel cointegration tests
Series: LX - LD - LPUE Sample: 1988 2008 Included observations: 168 Cross-sections included: 8
Null Hypothesis: No cointegration
Automatic lag length selection based on SIC with a max lag of 3
Newey-West automatic bandwidth selection and Bartlett kernel
Pedroni’s Test (Residual Cointegration Test) Trend assumption: Deterministic intercept and trend
Alternative hypothesis: common AR coefs. (within-dimension)
Statistic Prob. Weighted Statistic Prob.
Panel v-Statistic 0.714735 0.2374 0.116556 0.4536
Panel rho-Statistic -0.417653 0.3381 0.240157 0.5949
Panel PP-Statistic -3.395447 0.0003 -2.978726 0.0014
Panel ADF-Statistic -3.452005 0.0003 -3.052121 0.0011
Alternative hypothesis: common AR coefs. (within-dimension)
Statistic Prob
Group rho-Statistic 0.851300 0.8027
Group PP-Statistic -2.709311 0.0034
Group ADF-Statistic -2.610142 0.0045
Kao’s Test (Residual Cointegration Test) Trend assumption: No deterministic trend
Alternative hypothesis: common AR coefs. (within-dimension)
Statistic Prob.
ADF -1.627718 0.0518
Residual variance 0.061223
HAC variance 0.031124
Johansen Test (Fisher Panel Cointegration Test) Trend assumption: Linear deterministic trend
Lags interval (in first differences): 1 1
Unrestricted Cointegration Rank Test (Trace and Maximum Eigenvalue)
HypothesizedNo. of CE(s)
Fisher Stat.*(from trace test) Prob.
Fisher Stat.*(from max-eigen test) Prob.
None 51.44 0.0000 38.41 0.0013
At most 1 27.00 0.0415 24.72 0.0750
At most 2 21.45 0.1618 21.45 0.1618
* Probabilities are computed using asymptotic Chi-square distribution.
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3.2 Estimation Method
The following specifications will be estimated hereafter:
- First, an autoregressive distributed lag (ADL) model in level will
be estimated (assuming stationarity of the series), by using two
alternative specifications for relative prices: one based on prices
in the EU and that based on competitor prices on the European
market;
- Second, an autoregressive distributed lag (ADL) model will be
estimated in first differences (assuming non-stationarity of the
series), by using the two alternative specifications for relative
prices; and.
- Lastly, an -error-correction model (ECM) will be estimated in one
step, which helps to include integrated and non-cointegrated
cases, still under the two alternative specifications of relative prices.
3.3 Key Outputs
3.3.1. ADL model in level in the case of EU prices (LPUE)
The key outcomes of the panel estimation are summarized in Table 8:
• The estimated value of elasticity of demand for exports stands
at 0.82 in the long run and 0.27 in the short run.
• A significantly positive trend ensues from these estimations,
which represents a market share growth trend.
• Price elasticities bear the expected sign: the value of such
elasticity stands at -0.71 in the short run and long run.
• The ADL model has satisfactory statistical properties.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 13: Estimation of Exports in Level in the Case of EU Prices
Dependent Variable: LX
Method: Panel Least Squares
Sample (adjusted): 1989-2008
Periods included: 20
Cross-sections included: 8
Total panel (balanced) observations: 160
Cross-section SUR (PCSE) standard errors & covariance (d.f. corrected)
Variable Coefficient Std. Error t-Statistic Prob.Constant 3.679917 0.729487 5.044528 0.0000
LX(-1) 0.677151 0.071589 9.458823 0.0000
LD 0.265131 0.096423 2.749664 0.0067
LPUE -0.705671 0.079139 -8.916812 0.0000
LPUE(-1) 0.475012 0.087979 5.399130 0.0000
Trend 0.037081 0.008620 4.301492 0.0000
Effects SpecificationCross-section fixed (dummy variables)
R-squared 0.976254 Mean dependent var 12.44637
Adjusted R-squared 0.974316 S.D. dependent var 1.413753
S.E. of regression 0.226571 Akaike info criterion -0.053759
Sum squared resid 7.546150 Schwarz criterion 0.196099
Log likelihood 17.30074 Hannan-Quinn criter. 0.047699
F-statistic 503.6370 Durbin-Watson stat 2.302661
Prob(F-statistic) 0.000000
Source: ITCEQ/DEFI Calculations
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Graph 18 below illustrates the static adjustment on the past of this ADL model.
3.3.2. ADL model in levels in the case of competitor prices(LPCON)
The key outcomes for this model are summarized in Table 14:
• The value of elasticity of demand for exports stands at 0.83
in the long run and 0.26 in the short run.
• A significantly positive trend ensues from these estimations,
which represents a market share growth trend in this sector.
• Estimated price elasticities stand at -0.65 in the short run and
-0.71 in the long run.
• The statistical properties of the residuals of this equation are
satisfactory.
Hence, there is little difference between both specifications: that
which retains EU prices in the relative price and that which uses
competitor prices on the European market.
Source: ITCEQ/DEFI Calculations
Graph 18: Tunisian Exports observed and adjusted (in log)
119
Graph 19 illustrates the static adjustment on the past of this ADL model.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 14: Level export estimates in the case of competitor prices
Dependent Variable: LX
Method: Panel Least Squares
Sample (adjusted): 1989-2008
Periods included: 20
Cross-sections included: 8
Total panel (balanced) observations: 160
Cross-section SUR (PCSE) standard errors & covariance (d.f. corrected)
Variable Coefficient Std. Error t-Statistic Prob.Constant 3.532320 0.689397 5.123782 0.0000LX(-1) 0.688561 0.073388 9.382525 0.0000LD 0.258474 0.099060 2.609279 0.0100LPUE -0.645157 0.079857 -8.078912 0.0000LPUE(-1) 0.423191 0.084779 4.991701 0.0000Trend 0.025265 0.008747 2.888411 0.0045
Effects SpecificationCross-section fixed (dummy variables)R-squared 0.974836 Mean dependent var 12.44637Adjusted R-squared 0.972782 S.D. dependent var 1.413753S.E. of regression 0.233240 Akaike info criterion 0.004265Sum squared resid 7.996959 Schwarz criterion 0.254122Log likelihood 12.65883 Hannan-Quinn criter. 0.105723F-statistic 474.5551 Durbin-Watson stat 2.356153Prob(F-statistic) 0.000000
Source: ITCEQ/DEFI Calculations
Source: ITCEQ/DEFI Calculations
Graph 19: Tunisian exports observed and adjusted (in log)
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3.3.3. ADL model in first differences in the case of EUprices (DLPUE)
The key outcomes for this model are summarized in Table 15:
• The export demand variable is not statistically significant.
• Price elasticities bear the expected sign, and the value of this
elasticity stands at -0.67 in the short run and -0.70 in the long run.
• This model has satisfactory statistical properties. However,
this specification seems to be less relevant on account of the
non-significant value of the demand parameter.
Hence, while it is true that this model is in principle less relevant than
the previous ones, it is worth noting also that the value of price elasticities
is of a comparable order of magnitude, both in the long and short terms.
Table 15: Export equation estimates of growth rates in the case of EU prices
Dependent Variable: DLX
Method: Panel Least Squares
Sample (adjusted): 1990- 2008
Periods included: 19
Cross-sections included: 8
Total panel (balanced) observations: 152
Cross-section SUR (PCSE) standard errors & covariance (d.f. corrected)
Variable Coefficient Std. Error t-Statistic Prob.
Constant 0.064636 0.022456 2.878397 0.0046
LX(-1) -0.310827 0.125930 -2.468259 0.0148
DLD 0.311570 0.210593 1.479487 0.1413
DLPUE -0.674955 0.084278 -8.008625 0.0000
DLPUE(-1) -0.237546 0.107686 -2.205923 0.0290
Effects SpecificationCross-section fixed (dummy variables)
R-squared 0.462975 Mean dependent var 0.052422
Adjusted R-squared 0.420780 S.D. dependent var 0.313173
S.E. of regression 0.238345 Akaike info criterion 0.045462
Sum squared resid 7.953167 Schwarz criterion 0.284189
Log likelihood 8.544923 Hannan-Quinn criter. 0.142441
F-statistic 10.97231 Durbin-Watson stat 2.140882
Prob(F-statistic) 0.000000
Source: ITCEQ/DEFI Calculations
121
Graph 20 illustrates the static adjustment on the past of this ADL model.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
3.3.4. ADL model in first differences in the case of competitor
prices (DLPCON)
The key outcomes for this model are summarized in Table 16:
• The export demand variable is not statistically significant.
• Price elasticities bear the expected sign, and the value of this
elasticity stands at -0.58 in the short run and -0.62 in the long run.
• The estimated model has satisfactory statistical properties.
However, this specification, as in the previous case, seems to
be less relevant than level estimates on account of the non-
significant value of the demand parameter.
Source: ITCEQ/DEFI Calculations
Graph 20: Annual Growth Rate of Tunisian Exports observed and adjusted
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Table 16: Estimating Exports Equations (ECM) in the case of EU prices
Dependent Variable: DLX
Method: Panel Least Squares
Sample (adjusted): 1990- 2008
Periods included: 19
Cross-sections included: 8
Total panel (balanced) observations: 152
Cross-section SUR (PCSE) standard errors & covariance (d.f. corrected)
Variable Coefficient Std. Error t-Statistic Prob.Constant 0.071608 0.022456 2.878397 0.0053LX(-1) -0.321674 0.125930 -2.468259 0.0136DLD 0.104188 0.210593 1.479487 0.6341DLPCON -0.581546 0.084278 -8.008625 0.0000DLPCON(-1)) -0.238305 0.107686 -2.205923 0.0212Effects SpecificationCross-section fixed (dummy variables)R-squared 0.426061 Mean dependent var 0.052422Adjusted R-squared 0.380966 S.D. dependent var 0.313173S.E. of regression 0.246401 Akaike info criterion 0.111940Sum squared resid 8.499850 Schwarz criterion 0.350667Log likelihood 3.492579 Hannan-Quinn criter. 0.208919F-statistic 9.448029 Durbin-Watson stat 2.141201Prob(F-statistic) 0.000000
Source: ITCEQ/DEFI Calculations
Source: ITCEQ/DEFI Calculations
Graph 21: Annual Growth Rate of Tunisian Exports observed and adjusted
Graph 21 illustrates the static adjustment on the past of this ADL model.
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3.3.5. Error-Correction Model (ECM) in the case of EUPrices (LPUE)
The key outcomes for this model are summarized in Table 17:
• The export demand variable is not statistically significant in
the short term. The value of elasticity of demand for exports
stands at 0.98 in the short run, and is not significantly different
from the unit value.
• Price elasticities bear the expected sign, and the value of this
elasticity stands at -0.73 in the short run and -0.61 in thelong run.
• The ECM has satisfactory statistical properties.
Dependent Variable: DLX
Method: Panel Least Squares
Sample (adjusted): 1990- 2008
Periods included: 20
Cross-sections included: 8
Total panel (balanced) observations: 160
Cross-section SUR (PCSE) standard errors & covariance (d.f. corrected)
Variable Coefficient Std. Error t-Statistic Prob.
Constant 2.280052 0.556009 4.100751 0.0001
DLPUE -0.729278 0.086822 -8.399715 0.0000
DLD 0.360015 0.215213 1.672830 0.0965
LX(-1)-LD(-1)-LPUE(-1) -0.219796 0.066134 -3.323475 0.0011
LD(-1) 0.020319 0.054852 0.370431 0.7116
LPUE(-1) -0.385218 0.118384 -3.253987 0.0014
Effects SpecificationCross-section fixed (dummy variables)
R-squared 0.466462 Mean dependent var 0.057073
Adjusted R-squared 0.422908 S.D. dependent var 0.308321
S.E. of regression 0.234221 Akaike info criterion 0.012656
Sum squared resid 8.064344 Schwarz criterion 0.262513
Log likelihood 11.98755 Hannan-Quinn criter. 0.114114
F-statistic 10.70996 Durbin-Watson stat 2.387917
Prob(F-statistic) 0.000000
Source: ITCEQ/DEFI Calculations
Table 17: Estimating Exports Equations (ECM) in the case of EU prices
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Graph 22 illustrates the static adjustment on the past of this ADL model.
Source: ITCEQ/DEFI Calculations
Graph 22: Annual Growth Rates of Tunisian Exports observed and adjusted
3.3.6. Error-Correction Model (ECM) in the case ofCompetitor Prices (LPCON)
The key outcomes for this model are summarized in Table 18:
• The export demand variable is not statistically significant in
the short term. The value of elasticity of demand for exports
stands at 0.99 in the short run, and is not significantly different
from unity.
• Price elasticities bear the expected sign, and the value of this
elasticity stands at -0.67 in the short run and -0.49 in the long run.
• The ECM has satisfactory statistical properties.
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T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Dependent Variable: DLX
Method: Panel Least Squares
Sample (adjusted): 1990- 2008
Periods included: 20
Cross-sections included: 8
Total panel (balanced) observations: 160
Cross-section SUR (PCSE) standard errors & covariance (d.f. corrected)
Variable Coefficient Std. Error t-Statistic Prob.
Constant 2.982117 0.652054 4.573424 0.0000
DLPCON -0.673427 0.080996 -8.314298 0.0000
DLD 0.136647 0.214470 0.637140 0.5250
LX(-1)-LD(-1)-LPUE(-1) -0.260304 0.068674 -3.790439 0.0002
LD(-1) 0.014654 0.058726 0.249525 0.8033
LPCON(-1) -0.511016 0.122944 -4.156494 0.0001
Effects SpecificationCross-section fixed (dummy variables)
R-squared 0.455845 Mean dependent var 0.057073
Adjusted R-squared 0.411424 S.D. dependent var 0.308321
S.E. of regression 0.236540 Akaike info criterion 0.032360
Sum squared resid 8.224823 Schwarz criterion 0.282218
Log likelihood 10.41120 Hannan-Quinn criter. 0.133819
F-statistic 10.26198 Durbin-Watson stat 2.388638
Prob(F-statistic) 0.000000
Source: ITCEQ/DEFI Calculations
Table 18: Estimating Exports Equations (ECM) in the case of EU prices
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T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
In conclusion, the data panel estimates helped to meaningfully
supplement the estimates made for each sector considered separately.
Given the low number of observations in the sample studied, data
panel estimation allows for a rather robust estimation of the 'average'
dynamic behaviour of sector exports. It follows that, whatever the
specifications used for the measurement of relative prices:
- The elasticity of Tunisian exports to Europe in relation to expressed
demand is close to unity in the long run (this unit value is not
statistically rejected in ECMs), but, on average, seems relatively
low in the short term and even non-significant in growth rate
estimates. As a result, the instantaneous effect of a variation in
expressed demand may be considered negligible, given that
sector export adjustments probably require a time frame
substantially greater than one year;
- The price elasticity of Tunisian exports to Europe stands at -0.6
to -0.73 both in the short and long terms;
- Lastly, the residual plots of the various models estimated suggest
that the IAA, IMCCV (the first sub-period) and hydrocarbons
sectors are the least close to the overall estimate, which justifies
the sector approach developed in the previous section. Indeed,
it has been revealed in this section that the hydrocarbons sector
has much higher price elasticity than other sectors, while the
IAA sector has relatively high short-term demand elasticities
compared to other export sectors.
Graph 23 illustrates the static adjustment on the past of this ADL model.
Source: ITCEQ/DEFI Calculations
Graph 23: Annual Growth Rate of Tunisian Exports observed and adjusted
127
4. Possible Extensions of Econometric Analysis
4.1 A Foreign Trade Model (in volume and in price)
For each sector i, an import equation as well as export/import
price equation could supplement the modelling of Tunisia's
foreign trade.
4.1.1. Import Volume Function
The determinants usually adopted in the volume of imports are
domestic demand, a term in competitiveness formulated as the
relative price of domestic production compared to import prices
(usually calculated excluding energy) and a term in productive
capital utilization. Usually, the cyclical economic pressures on
production capacity are described by integrating this equation
into the utilization rates (UR) of domestic production capacity
relative to those of key partners. This ratio helps to identify a
possible supply constraint which is subject to the national
economy. The expected sign of its elasticity with respect to imports
is positive: when utilization rates are higher in Tunisia than in its
main partners, the increased domestic demand is directed towards
foreign producers, thereby increasing the volume of imports. If
this ratio comes out significantly in this relationship, its
consideration may, however, create some variational problems.
Lastly, some models enrich the analysis by incorporating non-
price competitiveness such as effort in research and development
(for example the integration of the age of capital).
The import function is written as follows:
Γi: the share of domestic products in domestic demand (household
consumption + investment by businesses) is a function of the ratio
between foreign and domestic prices (competitiveness effect).
4.1.2. Export Price Function
In fixing their prices (PX), Tunisian producers are alleged to have a
margin-driven attitude towards foreign and domestic markets alike.
Nevertheless, to cope with foreign competition, they also take
account of foreign prices (P*X) when setting export prices. Hence,
there is a trade-off between the margin-driven attitude (passing on
the total fluctuations in unit cost22 (CU) to export prices, so as to
maintain a constant profit margin), and a competitiveness-driven
attitude (passing on the total fluctuations in foreign prices to export
prices in a bid to maintain competitiveness). This trade-off translates
into a long-term target expressed as a weighted average of foreign
prices and domestic costs.
The import price function is written as follows:
19 An approximation of unit costs may be made by incorporating domestic production prices.
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A value ε1 in the upper end means the competitiveness-driven
attitude prevails over the margin-driven attitude.
4.1.3. Import Price Function
Importers conduct a trade-off similar to that of exporters: in order
to maintain profit margins, they index their selling price on Tunisian
territory to their production costs, approximated by foreign import
prices (P*M). However, in order to maintain their competitiveness in
relation to French commodities, they also take into account domestic
production prices (PVA). Unlike foreign export prices, the foreign
import price is derived from simple weighting, given that competition
takes place only on Tunisian territory and therefore does not take
third-country markets into account.
The import price function is written as follows:
4.2 VAR Modelling from the Cointegration Equation
Based on the cointegration equation presented in section I:
miT(t) = a0 y(t) + a1 [piE(t) - py(t) ] + a2 [piT(t) - piE(t) ] + c + ê(t)
It is possible to proceed with the estimation of a VAR model, in order
to conduct forecast exercises. In this case, the structure of the VAR
model could be as follows (given that lag orders may be higher):
ΔmiT(t) =
b11ΔmiT(t-1) + b21Δy(t-1) + b31Δ [piE(t-1) - py(t-1)] + b41Δ [piT(t-1) -
piE(t-1)] + c01 – β1ê(t-1) + ε1(t)
Δy(t) =
b12ΔmiT(t-1) + b22Δy(t-1) + b32Δ [piE(t-1) - py(t-1)] + b42 Δ [piT(t-1) -
piE(t-1)] + c02 – β2ê(t-1) + ε2(t)
Δ [piE(t) - py(t)]
= b13ΔmiT(t-1) + b23Δy(t-1) + b33Δ [piE(t-1) - py(t-1)] + b43Δ [piT(t-1) -
piE(t-1)] + c03 – β3ê(t-1) + ε3(t)
Δ [piT(t) - piE(t)]
= b14ΔmiT(t-1) + b24Δy(t-1) + b34Δ [piE(t-1) - py(t-1)] + b44Δ [piT(t-1) -
piE(t-1)] + c04 – β4ê(t-1) + ε4(t)
However, it is worth noting that estimating such a model for each
sector is a huge task, and it is probably possible only after a selection
of the most important sectors for analysis (or considering only Tunisian
exports to Europe as a whole).
4.3 Non-linearities
The long-term structural equation for imports:
miT(t) = a0 y(t) + a1 [piE(t) - py(t) ] + a2 [piT(t) - piE(t) ] + c + ê(t)
hinges on the assumption of constant elasticities. However, various
forms of non-linearities or structural changes may be considered.
4.3.1. Temporal variation in income elasticity
For example, one may consider that income elasticity depends on
the European economy: in the early stages of the economic cycle
(for example, when unemployment rate u is higher than the natural
rate û), the income elasticity may be higher than in the low phases
of the cycle (when the unemployment rate is below the natural
rate).In order to model this process, a formalization based on
nonlinear smooth transition models (Smooth Transition) may be
proposed.
Suppose the following transition function, bound between 0 and 1,
wherein u(t) stands for the European unemployment rate, û the
natural unemployment rate and g>0 a parameter driving the velocity
of transition between regimes:
G(u(t) , g , û) =
It is established that if the unemployment rate is much higher than
129
the natural rate (on the brink when g.[u(t)-û] tends to infinity, which
is a mere mathematical assumption), function G tends towards
0, whereas when unemployment rate is much lower than the
natural rate (on the brink when g.[u(t)-û] tends towards minus
infinity, which is yet a mere mathematical assumption), function
G tends towards 1.
The proposed transition function helps to model a change in income
elasticity with respect to the European cycle of activity.
Indeed, the import equation may then be written as follows:
miT(t) = d0 y(t) + G.d1.yt + a1 [piE(t) - py(t)] + a2 [piT(t) - piE(t) ] + c + ê(t)
with: G =
Given that the value of G depends on the European unemployment
rate, the estimation of this equation will help to obtain income elasticity
values that necessarily range between d1+d0 (whenever the
unemployment rate is trending low) and d0 (whenever the
unemployment rate is trending high)23 .
The graph below represents a hypothetical simulation of income
elasticity engendered by such modelling wherein various values of
the unemployment rate are considered u(t) between 1% and 13%
and for the values of parameters fixed as follows:
g=50, û=6%, d0=0.1, d1 = 1.5.
At the econometric level, the estimation of the previous model may
be conducted through the non-linear least-squares method or the
least likelihood method, with a view to determining the values of
unknown d0, d1, a1, a2, c, g and û.
4.3.2. Temporal variation in price elasticity
The price elasticity of foreign trade may depend on the absolute
difference between Tunisian export prices and competitor export
prices piT(t) - piE(t).
Indeed, when the price differential is small, i.e. when [piT(t-1) -
piE(t-1)]² is close to zero (or a given threshold k), the price elasticity
of Tunisian exports may be assumed to be relatively low, whereas
when the price differential is huge, i.e. when [piT(t-1) - piE(t-1)]² departs
significantly from zero (or a threshold k), Tunisian exports will be
heavily dependent on fluctuations in relative prices.
In order to model such phenomenon, the following formalization
may be proposed:
Suppose the transition function G (.), bound between 0 and 1, where
in [piT(t-1) - piE(t-1)] stands for price differential, k the threshold beyond
which it is advantageous for consumers to change the content of
their consumption basket and h> 0 a parameter driving the velocity
of transition between regimes:
G([piT(t-1) - piE(t-1)] , h , k) =
23 Given that the unemployment rate ranges between 0 and 1, an alternative would consist in simply replacing function G with the unemployment rate observed. However,the proposed transition function has the advantage of taking into account broader transition variables than the unemployment rate, and which are not bound between 0and 1.
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It is established that when the price differential is very high (positively
or negatively) with respect to the threshold k (on the brink as –h{[piT(t-
1) - piE(t-1)]² - k} tends to infinity), function G tends to 1, whereas when
the price differential remains low (in the sense that the distance between
the price remains close to the threshold k), function G tends to 0.
Hence, the proposed transition function makes it possible to model
a change in price elasticity based on the absolute difference in
relative prices.
Thus, the import equation can then be written as follows:
miT(t) = a0 y(t) + a1 [piE(t) - py(t) ] + f0 [piT(t) - piE(t) ] + G. f1 [piT(t) - piE(t)
]+ c + ê(t)
with: G =
Since the value of G depends on the absolute difference in relative
prices, the estimation of this equation will yield price elasticity values
between f1+f0 (to which it tends when the price differential is high)
and f0 (toward which it tends when the spread between the prices
is small).
The graph below represents a simulation of income elasticity
engendered by such modelling wherein various values of the price
differential are considered between -35% and 35% and for the
values of parameters fixed as follows: h=15, k=0, f0=-0.1, f1 = -1.5.
As in the previous case, the estimation of the model may be carried
out by the non-linear least squares method or maximum likelihood
method to determine the value of unknown parameters f0, f1, a0, a1,
c, h and k.
4.4 Quantitative Rationing by Supply or Demand
It has been stated in the foregoing that the Tunisian sector export
equation:
miT(t) = a0 y(t) + a1 [piE(t) - py(t) ] + a2 [piT(t) - piE(t) ] + c
actually describes a Europe-driven demand equation. From this
perspective, it may be relevant to define such demand equation by
stating it:
(4) DmiT(t) = a0 y(t) + a1 [piE(t) - py(t) ] + a2 [piT(t) - piE(t) ] + c
Similarly, the sector’s export supply (i) is conventionally modelled
as24:
SMiT(t) = γS YiT(t) [PiTX(t) / PiTX(t)]σT
Where:
SMiT(t): Tunisian export volume supply of commodity (i)
YiT: Tunisian total production volume of commodity (i)
PiTD: price index of commodity (i) on the Tunisian domestic market
(in local currency)
PiTX: Tunisian export price index of commodity (i), in local currency.
24 cf. Annabi and al., 2003.
131
γS: scale parameter
σT: verifying elasticity of processing σT>0
Suppose, in logarithms:
(5) SmiT(t) = yiT + σT [piTX(t) - piTX(t)] + c1
In the case of perfect price flexibility, the balance between supply
(7) and demand (6) will be achieved through an appropriate
adjustment of export prices25. However, if it is assumed that there
is some export price rigidity, the quantity exported will stand at least
between supply (6) and demand (7).
An achievable estimation of a quantitative rationing model of this
type may be conducted through a CES function as follows:
(6)
wherein the supply and demand functions are defined by
equations 6 and 7. Indeed, for large values of parameter ρ, the
CES function operates as operator Min.
The graph below illustrates the behaviour of the CES function with
respect to two time-varying variables S and D, where ρ = 100. It
can be observed that the CES function goes well with the minimum
of S and D.
Although the estimation of a CES function is not hitch-free, it may
be possible to econometrically estimate equation 8, in conjunction
with defining equations 6 and 7.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
!
25 However, it is worth noting that PiTX differs from PiT, given that it does not factor in foreign exchange conversion, nor customs duties nor other costs borne by Europeanimporters of commodity i
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T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
This study sought to lay the groundwork for the modelling of
Tunisian sector exports towards the European market.
In the medium term, the completed study should help to carry
out medium-term forecasts (conditionally using international
environment scenarios) and provide decision makers with some
key guidelines to economic and industrial policies with a view to
enhancing the dynamics of Tunisia’s exports.
Indeed, quantitatively speaking, this analysis led to the identification
of areas most sensitive to changes in relative prices. From this
perspective, the orientation of specialization towards goods that
are less standardized, but more specific in terms of quality, should
reduce the sensitivity of certain exports to relative prices (this is
particularly true of the Textile, Apparel and Leather Sector and the
Chemical Industries Sector).
In the shorter term, these sectors would prove most sensitive to
deterioration in price competitiveness, which should guide policy
discussions aimed at improving their competitiveness. In addition,
the Hydrocarbons Sector, which turns out to be the most sensitive
to changes in relative prices, remains a very specific case due to
the standardized nature of its commodities.
With respect to elasticities of short-term demand, it was
demonstrated that the most sensitive sector is the Agri-food industry.
As a result, it is obviously most vulnerable to cycles in the global
economy. Nevertheless, it would be strategically profitable to
develop this sector's exports for the world's most dynamic
domestic markets.
Lastly, some modelling avenues were proposed as possible
extensions of the econometric analysis. At this stage, attempts to
estimate these models have proven to be problematic. According
to the RESET tests applied to various sectors, assumptions of non-
linearities were rejected, whereas the estimates of VAR models and
quantitative rationing models did not prove conclusive. Nevertheless,
these avenues deserve to be explored in future research works.
Conclusions
133
Bibliography
Annabi N., Cockburn J., Decaluwé B. (2003), Formes
Fonctionnelles et Paramétrisation dans les MCEG, CREFA,
Université de Laval.
De Boeff, S. (2000), Modeling Equilibrium Relationships: Error
Correction Models with Strongly Autoregressive Data, Political
Analysis, Vol 9, 14-48.
Dickey, D.A., and Fuller, W.A. (1981), Likelihood Ratio Statistics for
Autoregressive Time Series with a Unit Root, Econometrica, Vol 49,
pp 1057-72.
Engle, R.F., and Granger, C.W.J. (1987), 'Cointegration and error
correction: representation, estimation and testing, Econometrica,
Vol 55, pp 251-276.
Hurlin, C. (2001), L’Econométrie des Données de Panel, Ecole
Doctorale Edocif, Séminaire Méthodologique.
Narayan P.K. (2004), Reformulating Critical Values for the Bounds
F-statistics Approach to Cointegration: An Application to the Tourism
Demand Model for Fiji. Discussion Papers No. 02/04 Monash
University.
Pesaran, M.H., Shin, Y., and Smith, R.J. (2001), Bounds testing
approaches to the analysis of level relationships. Journal of Applied
Econometrics, Vol 16, pp 289-326.
Wong, K. N. (2008), Disaggregated export demand of Malaysia:
evidence from the electronics industry. Economics Bulletin, Vol.
6, No. 6 pp. 1-14.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Chapter III
Analysis of the Demand for Tunisian Goods
135
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table of Contents
136 Introduction
136 1. Stage One
141 2. Stage Two
145 3. Industry-by-Industry Analysis
136
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Introduction
The purpose of the analysis is to identify "promising"
commodities for Tunisia. The methodology followed comprises
two major parts. In the first part, potentially "significant"
commodities for Tunisia are identified. The typology is based on
four main criteria: level of exports (global and vis-à-vis the European
Union) by Tunisia; level of revealed comparative advantage (RCA);
and variation in exports and revealed comparative advantage. For
variations (either of exports or RCA), the reference period is 2003-
2008, so as to better identify the dynamics involved. With respect
to levels, the calculation was done by taking the mean between
2006 and 2008, with a view to eliminating business cycle variations.
From the COMTRADE database at the most disaggregated level
(6-digit), and using the 4 criteria, 30 industries were identified,
which together account for 25% of Tunisia's exports in 2008.
While the first stage focuses on Tunisian supply, the second stage
lays emphasis on demand. Consequently, the changes in supply
for each of the 30 industries were analysed.
1. Stage one
The industry list given in Table 1 below provides relevant information
on the industries and other issues of interest. First, at the most
aggregate level, there are 7 agri-foodindustries (HS01 - HS23), 3
inorganic chemical industries (HS28; phosphates), and several W
"commodities" derived from iron and steel (HS72), and electrical
machinery (85). Almost all of these industries have a positive
trade balance and for most of them, the import level is very low.
They are mainly exporting industries, with very low intra-industry
trade. Regarding the level of exports, 4 industries account fort a
significant share (12%) of Tunisian exports: 150910, 280920,
310310, and 853690. Lastly, it is noticeable that all the industries
selected have a positive and very high revealed comparative
advantage, except for 852812.
In order to better appraise the significance and trends of these
30 industries, they were sorted by level of importance among
Tunisian Exports and then divided into three groups. The following
pages contain graphs, each for one of the three groups. For all
industries, the graphs are for the period 2000-2009. There are
three graphs for each industry group: one shows the evolution of
exports (and then it also gives the opportunity to see the sharp
drop in trade due to the financial crisis), the second shows the
change between 2003 and 2008 and the third shows the trend
of the revealed comparative advantage.
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T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Product Product Name RCA Exports Trade Balance Exp.Share
030239 Tunas skipjack or stripe-bellied bonito... 0.96 58,382.56 58,381.12 0.30%
040630 Processed cheese, 0.81 29,775.37 28,811.48 0.15%
150910 Virgin 0.98 574,217.43 572,761.60 2.97%
150990 Other 0.93 46,095.95 46,053.40 0.24%
151000 Other oils..... 0.97 27,738.70 23,783.47 0.14%
151710 Margarine, excluding liquid margarine 0.87 38,352.88 38,352.31 0.20%
230690 Other 0.93 9,216.26 9,216.26 0.05%
251010 Unground 0.94 147,511.96 147,511.96 0.76%
280920 Phosphoric acid and polyphosphoric acids 0.97 725,131.54 639,897.35 3.75%
283525 Phosphates: Calcium hydrogenorthophosphate 0.98 64,320.84 64,298.90 0.33%
283526 Phosphates:-- Other phosphates of calcium 0.97 90,545.08 90,523.38 0.47%
310310 Superphosphates 0.99 626,892.66 626,892.66 3.25%
520839 Dyed :-- Other fabrics 0.76 11,031.69 -40,415.97 0.06%
611249 Women's or girls' swimwear 0.99 35,060.86 33,570.27 0.18%
621010 Of fabrics of heading No. 56.02 or 56.03 0.97 158,879.24 146,244.53 0.82%
721030 Electrolytically plated or coated with zinc 0.52 22,776.00 19,676.60 0.12%
721049 Otherwise plated or coated with zinc 0.59 116,334.99 91,388.48 0.60%
721491 Other :-- Of rectangular cross-section 0.65 14,617.94 5,840.73 0.08%
740620 Powders of lamellar structure; flakes 0.97 20,300.78 20,244.92 0.11%
847190 Other 0.80 81,425.79 72,110.28 0.42%
851750 Other apparatus, for carrier-current line systems or for digit... 0.80 161,590.92 139,091.27 0.84%
852812 Reception apparatus for television 0.23 170,515.88 165,936.32 0.88%
853180 Other apparatus 0.93 68,192.05 63,597.62 0.35%
853690 Other apparatus 0.87 578,730.27 191,882.98 3.00%
854430 Ignition wiring sets and other wiring sets 0.70 172,225.15 -10,089.72 0.89%
854459 Other electric conductors 0.76 239,581.68 192,839.69 1.24%
854890 Other 0.87 89,169.01 69,144.95 0.46%
902830 Electricity meters 0.89 36,870.47 36,411.57 0.19%
961210 Ribbons 0.84 25,165.10 14,132.50 0.13%
961390 Parts 0.98 22,963.88 20,068.90 0.12%
Total ######### 3,578,159.80 0.23%
Table 1: Key Industries in Tunisia
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Graph 1.a: Evolution of exports of the key industriesTop 10 industries
Graph 1.b: Tunisia Exports to World 2003, 2008Top 10
Graph 1.c: Tunisia RCA with World 2000-2009Top 10
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Graph 2.a: Evolution of exports of the key industriesTop 11-20
Graph 2.b: Tunisia Exports to World 2003, 2008Top 11-20
Graph 2.c: Tunisia RCA with World 2000-2009Top 11-20
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T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Graph 3.a: Evolution of exports of the key industriesTop 21-30
Graph 3.b: Tunisia Exports to World 2003, 2008Top 21-30
Graph 3.c: Tunisia RCA with World 2000-2009Top 21-30
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2. Stage Two
After identifying potentially successful industries with respect to
Tunisian supply, the second stage attempts to assess the demand
trend and compare it with Tunisian supply.
First, there is a change in global demand for the 30 industries
identified, as shown in the graph below:
Graph 4: World Imports from World 2003, 2008
The graph describes global imports for these products for two years,
2003 and 2008, and the relative level of, and variation in, the demand
for each commodity. Five industries have a global demand much higher
than the rest: (721049, 852812, 853690, 854430, and 8545459).
Industries for which demand has increased the most are 251010, 230690,
310310, 854459, and 280920. For each of these five industries, global
demand has increased by more than 300%. During this period, the
increase in total global imports was a little over 110%. Twelve industries
had higher demand and two industries (030239, 851750) experienced
a decline in global demand (34% and 43%). See also table below.
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T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Reporter Product Product Name 2003 2008 2008 % Variation
0 030239Tunas (of the genus Tunnus) skipjack or stripe-bellied bonito (Euthynnus (Katsuwonus) pelamis),exc lunding livers and roes : -Other
556,830.991 366,877.877 -0,341
0 040630 Processed cheese, not grated or powdred 1,310,064.957 2,383,704.616 0.820
0 150910 Virgin 2,534,737.640 4,907,778.465 0.936
0 150990 Other 788,101.796 1,256,834.297 0.595
0 151000
Other oils and theirfractions, obtained solely fromolives, wether or not refined, but not chemiccalymodified, including blends of these oils or fractionswith oils or fractions of heading N°.15.0
85,354.027 230,863.345 1.705
0 151710 Margarine, excluding liquid margarine 742,651.639 1,624,874.252 1.188
0 230690 Other 65,728.005 303,258.366 3.614
0 251010 Unground 741,393.439 3,792,910.516 4.116
0 280920 Phosphoric acid and polyphosphoric adds 1,760,366.957 7,202,665.315 3.092
0 283525Phosphates: -calcium hydrogenorthophosphate(“dicalcium phosphate”)
264,012.468 633,375.252 1.399
0 283526 Phosphate:-other phosphates of calcium 297,946.680 1,059,238.644 2.555
0 310310 Superphosphates 627,845.727 2,700,043.471 3.300
0 520839 Dyed:-other fabrics 682,166.423 742,462.914 0.088
0 611249Women’s or girls’ swimwear:-of other textilematerials
63,634.259 64,613.937 0.015
0 621010 Of fabrics of heading N°. 56.02 or 56.03 951,616.144 1,488,329.897 0.564
0 721030 Electrolytically plated or coated with zinc 3,541,817.987 7,085,701.724 1.001
0 721049 Otherwise plated or coated with zinc:-other 9,291,254.117 22,466,215.247 1.418
0 721491Other:-of rectangular (other than square) cross-section
751,400.926 2,279,521.149 2.034
0 740620 Powders of lamellar structure; flakes 112,428.911 132,925.421 0.182
0 847190 Other 4,831,012.368 6,967,781.969 0.442
0 851750Other apparatus, for carrier-current line systemsor for digital line systems
17,359,352.886 9,886,454.734 -0.430
0 852812
Reception apparatus, for teleevision, whether ornot incorporating radio-broad cast receivers orsound or video recording or reproducing appa-ratus:-colour
26,404,762.434 78,694,420.177 1.980
0 853180 Other apparatus 2,038,031.989 2,282,609.436 0.120
0 853690 Other apparatus 16,462,291.070 31,350,854.230 0.904
0 854430Ingnition wiring sets and other wiring sets of akind used in vehicules, aircraft or ships
14,839,577.745 23,516,802.519 0.585
0 854459Other electric conductors, fora voltage exceeding80v but not exceeding 1,000 v:-other
5,282,229.260 22,222,484.002 3.207
0 854890 Other 2,761,272.151 3,242,141.436 0.174
0 902830 Electricity meters 822,344.712 1,658,544.995 1.017
0 961210 Ribbons 1,345,815.367 1,706,126.056 0.268
0 961390 Parts 101,217.088 142,548.323 0.408
Table 2: World trade with world 2003,2008
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Second, it is interesting to see which exporting countries are
(potentially) competitive with Tunisia. To achieve this, the industries
should be considered individually and collectively to identify countries
that are strong competitors in a number of key sectors. For the
industry-by-industry analysis, see section below.
To isolate the major competitors in the 30 sectors, the ten largest
exporters in the world were first identified, for 2008, and for each of
the sectors, and the number of appearances of each country as the
largest exporter or importer in the selected industries was counted.
Then, the following table shows all countries that emerge from this
analysis and appear at least five times. The first column gives the
number of times each country appears as one of the ten most
significant exporting countries and the second column shows the
number of times each country appears as one of the most significant
importing countries. Hence, the first line reveals that among the 30
countries identified, China is one of the major exporters (competitor?)
21 times, followed by Germany, France and the United States. It is
interesting that Tunisia stands out as one of the 10 most significant
countries for half of the industries - i.e. 15 times.
After identifying the "competitor" countries, it is interesting to assess
the level of similarity in the structure of exports between these
countries and Tunisia. The revealing indicator is Finger-Kreinin (FK).
It allows a comparison between the export structures of two
countries. If the structures are identical, FK is equal to "1", in case
both countries have totally different structures, which means there
is no commodity exported by both countries, FK is equal to "0".
Table 4 provides the FK between Tunisia and all countries identified
in the table above. It appears the level of similarity is highest with
Morocco and Mexico (0.346 and 0.334), followed by Turkey, and
then some European countries. The level of similarity is lowest with
Israel, Japan, Korea, and Taiwan. An indicator value of 0.346 can
be interpreted as a degree of similarity of export structures of
approximately 34.6%. As a benchmark, the level of similarity
between the U.S. and the EU is typically about 65%.
These statistics are very interesting. The level of similarity with all
countries (except Morocco and Turkey) increased. FK with
Morocco declined slightly over this period, indicating a
differentiation in specialization by both countries in different
commodities, but with almost no change recorded for Turkey.
The increase in similarity is most significant with Japan, Mexico,
and Israel. Given the level of change and similarity, it seems the
biggest competitors globally are some European countries (the
Czech Republic, France, Italy, Spain), and Morocco (but with a
decrease over the years).
The FK index considers the level of similarity between two countries
at the level of their exports structure. The RECPI index takes into
account the structure and level of exports. Supposing there are
two very similar countries, two cases are possible. In the first case,
the countries have nearly the same size, and in the second case,
there is a huge difference in size. FK does not measure or does
not capture this difference. This is done by RECPI which will then
report that the competitive pressure is likely to be much higher in
the second case as compared to the first. Hence, the table below
gives the RECPI for Tunisia and 18 countries by considering their
global exports. The greater the figure, the stronger the competitive
pressure.
Table 3: 2008 - Number of times each country appears asa principal exporter or importer
Country Export Count Import Count
CHN 21 8
DEU 18 21
FRA 16 23
TUN 15 2
USA 15 21
ITA 13 16
ESP 12 18
NLD 12 14
BEL 11 12
GBR 10 20
JPN 10
MEX 9 8
TUR 9 1
ISR 6 1
KOR 6 5
CZE 5 1
MAR 5 1
POL 5 7
TWN 5 3
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Table 4: FK Index between Tunisia and selected countries on exports to the world
Country 2003 2004 2005 2006 2007 2008
BEL 0.160 0.137 0.157 0.173 0.177 0.185
CHI 0.205 0.187 0.199 0.206 0.211 0.210
CZE 0.153 0.154 0.178 0.176 0.184 0.191
FRA 0.165 0.161 0.183 0.194 0.203 0.204
DEU 0.152 0.147 0.167 0.177 0.180 0.181
ISR 0.080 0.078 0.081 0.087 0.099 0.110
ITA 0.205 0.199 0.222 0.232 0.232 0.236
JPN 0.092 0.092 0.105 0.117 0.125 0.132
KOR 0.126 0.104 0.117 0.131 0.134 0.141
MEX 0.245 0.261 0.302 0.293 0.333 0.334
MAR 0.380 0.384 0.376 0.353 0.342 0.346
NLD 0.164 0.141 0.157 0.166 0.167 0.182
POL 0.174 0.166 0.192 0.198 0.200 0.202
ESP 0.192 0.188 0.206 0.214 0.217 0.231
TUR 0.268 0.250 0.267 0.270 0.267 0.265
GBR 0.207 0.194 0.212 0.225 0.238 0.251
USA 0.144 0.140 0.155 0.171 0.167 0.179
TWN 0.122 0.113 0.125 0.145 0.143 0.149
Table 5: Indice RECPI de la Tunisie et d’un groupe de pays concurrents
Country 2003 2004 2005 2006 2007 2008
BEL 3.36 1.99 2.48 3.18 2.19 2.55
CHI 4.95 3.65 4.82 5.62 4.08 3.99
CZE 0.33 0.27 0.37 0.39 0.30 0.35
FRA 2.52 1.56 2.04 2.55 1.56 1.72
DEU 4.04 3.10 3.82 4.52 2.95 2.80
ISR 0.12 0.07 0.06 0.07 0.06 0.12
ITA 3.39 2.31 2.77 3.32 2.33 2.22
JPN 1.44 1.21 1.49 1.81 1.36 1.68
KOR 2.08 1.30 2.08 2.86 1.93 2.59
MEX 9.07 9.30 13.44 14.73 13.01 11.04
MAR 0.48 0.39 0.36 0.33 0.22 0.41
NLD 4.02 2.10 3.02 4.20 2.87 3.72
POL 0.47 0.35 0.46 0.55 0.40 0.44
ESP 1.75 1.48 1.52 1.95 1.20 1.37
TUR 1.16 0.88 0.90 0.97 0.72 0.75
GBR 8.83 7.79 10.26 11.31 9.52 8.71
USA 3.94 2.45 3.27 4.64 3.01 4.78
TWN 1.24 0.87 1.28 1.70 1.12 1.23
The table reveals (generally) that the most competitive country is
Mexico, followed by the United Kingdom, the United States, China
and Nederland. It is interesting to note that the countries where
he competitive level increased the most are Korea, Japan and the
United States. In contrast, the competitive level decreased with
respect to most of the other countries.
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Table 6: Concurrents de la Tunisie par secteur
Country Mineral Fuels Electrical Machinery Apparel & Clothing Fertilisers Inorganic Chemicals
27 85 62 31 28
CZE 0.217 0.350 0.587 0.005 0.105
TUR 0.212 0.322 0.521 0.517 0.143
GBR 0.712 0.247 0.444 0.155 0.023
USA 0.244 0.231 0.468 0.575 0.070
BEL 0.254 0.265 0.513 0.077 0.172
CHI 0.306 0.237 0.461 0.307 0.134
FRA 0.214 0.342 0.434 0.032 0.016
DEU 0.214 0.284 0.504 0.010 0.024
ISR 0.217 0.139 0.283 0.219 0.300
ITA 0.246 0.316 0.442 0.078 0.033
JPN 0.214 0.216 0.426 0.006 0.023
KOR 0.213 0.167 0.259 0.226 0.038
MEX 0.911 0.298 0.501 0.750 0.183
MAR 0.212 0.360 0.509 0.742 0.660
NLD 0.218 0.221 0.540 0.041 0.060
POL 0.215 0.358 0.508 0.025 0.112
ESP 0.214 0.330 0.446 0.092 0.117
TWN 0.213 0.145 0.294 0.001 0.030
3. Industry-by-Industry Analysis
One of the industries with the strongest growth was 854459 (other
electrical conductors). Under the period 2006-08, this industry
was the 25th industry exported by Tunisia in 2006 and 13th in
2008, with an export share which increased from 0.81% to 1.24%
and an export growth rate slightly above 150%. The standardized
relative comparative advantage index also increased significantly
from 0.51 to 0.76, starting 2003.
The table below shows the 20 largest exporters of the world (and then
potentially the most significant competitors, as well as the 20 largest
importers of the world (which shows where the highest demand for
this industry is), and finally the 20 most important destinations for that
industry for Tunisia. The table also gives the rank for each of the latter,
including the percentage change in trade between 2006 and 2008.
There are several interesting aspects in this table. First, it is noticeable
that 14 of the largest exporters are also major importers. This may
The table below reviews the level of similarity, by sector, for the five
largest Tunisian exports sectors at 2-digit HS level. They account
for over 60% of exports. For each of these sectors, the comparison
involves the level of similarity between Tunisia and the 18 countries
identified as key competitors. In the table, for each sector, the five
countries with the highest level of similarity are shown in red, and
the most significant in "bold". There are noticeable differences among
the sectors regarding the most significant competitors. Morocco is
one of the 5 most significant competitors in four sectors; and 3
countries, namely: Turkey, Belgium, and China in 3 areas. However,
the variance is quite high across sectors. If "Electrical Machinery" is
taken into consideration, many countries will have fairly identical
levels of similarity. However, as regards the inorganic chemicals
sector, Morocco stands out as probably the biggest competitor.
Consequently, it is important to consider the policies in these countries
and the development of their trade in key sectors when formulating
subsequent relevant policies. To achieve this, a sector-by-sector
analysis is rather recommended, as shown in the section below.
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suggest that this is an industry/commodity where vertical integration
in "supply chains" is significant or an industry where, at the 6-digit
HS level, there is great horizontal differentiation. In the first case,
the high intersection between exporting and importing countries
suggests their involvement in the "value added chain." In the second
case, it suggests that it is an industry with highly differentiated
commodities, even at a highly disaggregated level.
Second, it is observed that the countries that posted the highest export
growth (above 200%) are Japan, Hungary, Austria, China, Turkey, the
United States and Norway. Those that recorded the highest import
growth are Romania, Mexico, China, Poland, Czech Republic, Slovakia
and Holland. Third, it is very interesting to see the intersection between
the main importers of the world and Tunisian export destination. Here,
there is an intersection with only six countries (Germany, Italy, France,
Austria, UK, and Belgium), all of which are European Union members.
This could perhaps suggest that this is an industry where Tunisia enjoys
good and increasing competitiveness, but fails to access the many
other markets. This could be for good reasons such as distance,
differences in demand, lack of knowledge of these markets on the part
of Tunisian exporters, etc., and may as well indicate the possibility of
barriers in other markets.
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World Tunisia
CZE 1 180 1 153 2 20339USA 2 217 2 145ITA 3 144 11 172 16 -79CHN 4 297 4 266POL 5 139 13 226FRA 6 169 5 150 1 221TUR 7 234JPN 8 262 12 158MEX 9 133 6 301CZE 10 176 14 237ESP 11 194AUT 12 284 8 135 11 NewGBR 13 125 3 133 9 -84KOR 14 197SWE 15 144BEL 16 173 17 196 10 354HUN 17 357CAN 18 109 7 172NLD 19 171 15 206NOR 20 204HKG 9 151ROM 10 479HUN 16 212SVK 18 258THA 19 144SGP 20 160GNQ 17 NewCOM 18 NewCMR 19 3019EGY 20 NewETH 3 441LBY 4 925DZA 5 178BFA 6 20IRQ 7 1373COG 8 32MLI 12 -18MDG 13 -48SEN 14 2006 onlyMAR 15 -87
Table 7: Exportations mondiales et tunisiennes vers un groupe de pays
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The table below shows Tunisian exports during the 2000s towards
the two most important destination countries for Tunisia (Germany
and France) and among the fifteen countries that are the world's
most significant importing countries, the eight countries that do not
appear as an important destination for Tunisia. It is noticed that
France is an important, long-standing destination for Tunisia, with
fairly sharp increase until 2008. By contrast, Germany has become
a popular destination in recent years. Furthermore, it would be very
interesting to look at Tunisia's sector exports compared to other
countries. It is revealed that for most of the years, and with respect
to most countries, Tunisia almost does not export, except for a very
low value in 2008.The latter may be random or may perhaps indicate
the export trend of this commodity towards a wider range of
countries.
Table 8: HS 854459: Tunisian Exports
Partner 2000 2001 2002 2003 2004 2005 2006 2007 2008
PRA 1,888.12 1,608.78 1,577.27 483.97 693.92 4,736.90 22,574.91 16,204.95 72,451.40
DEU 283.05 23.07 151.74 0.64 0.01 0.25 138.05 349.69 28,215.38
CAN 0.02 0.00 0.22 0.00
CHN 129.25 0.00 0.06 0.00 0.00
CZE 0.00 0.00 0.00 129.52
HKG 1.79
JPN 0.00 0.00 0.00 4.39
MEX 0.00 87.52
ROM 5.02
USA 47.20 0.00 0.00 0.00 127.93
Chapitre IV
Assistance for the Analysis of Tunisia’s Production System
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Table des matières
150 1. Summary of Work Done
150 1.1 Operation of individual databases
150 1.2 Determining a Methodological Framework for Analysing the Productivity Trend of the Tunisian Industry
152 2. Analysis of Outputs
152 2.1 Descriptive Analysis of Tunisia’s Industrial Business Database
164 2.2 Productivity Decomposition Analysis
164 2.2.1 Principle of Decomposition Methods
165 2.2.2 Outputs
171 3. conclusion
172 Bibliography
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1. Summary of Work Done
Following the first mission fielded in September, the emerging
needs of ITCEQ focused primarily on two points: (i) the operation
of individual databases; and (ii) the determination of a framework
analysis to study the labour productivity trend of Tunisian businesses.
1.1 Operation of individual databases
One of the major concerns of the ITCEQ team concerning the use
of individual databases is the problem of cleaning. This part of the
work is crucial, given that it determines the quality of outcomes and
the analysis that will be performed from these data. Moreover, it is
important to follow a rigorous procedure and control successive
changes in the base that ensue from the various stages of cleaning.
This procedure, which is programmed on Stata, requires time and
proper mastery of the software.
The procedure involves two major steps. The first is to prepare the
base on Stata (creation of a single base from various data files,
harmonization of questionnaires, interpolations, etc.). The second
step is "cleaning properly speaking” i.e., to remove outliers and
observations when key variables are not populated.
Technical assistance provided by DEFI team consisted in:
- First, presenting the methods for cleaning the databases of
businesses most commonly used in the literature (see slides in
Appendix);
- Second, presenting and explaining the main commands for
managing databases on Stata (see slides in Appendix); and
- Third, creating, under Stata, a single database containing all the
available data from surveys which were originally on separate
Excel files by year and by category of variables (status, outcome,
employment, liabilities, assets, capital assets, identification,
accounting values, book values and suite).
The transition from these Excel files to a full database on Stata would
require the:
- harmonization of all Excel files to make them comparable;
- establishment of correspondences between different
questionnaires (questionnaire change from 98);
- Addition of price indices; and
- merger of all these files so as to have a complete STATA
package..
- Fourth, developing, with the ITCEQ team, the cleaning procedure
programme in which many comments have been introduced so
that ITCEQ can not only use it but also modify it to their liking.
Key outputs of part one (I.1)
- ITCEQ executives trained on methods of cleaning
microeconomic data and on the management of databases on
Stata
- In terms of output, ITCEQ has (i) a comprehensive database
within Stata with all the variables available from the Survey over
a period of 11 years (1997-2007); and (ii) a cleaning programme
on Stata that was validated in unison during the last mission
in April.
I.2 Determining a Methodological Framework forAnalysing the Productivity Trend of the Tunisian Industry
Discussions during the first mission in Tunis led to the decision to
apply the productivity decomposition method. This method consists
151
in identifying the extent to which productivity gains are attributable
to productivity growth within businesses or to the phenomenon of
reallocation.
Technical assistance provided by DEFI team consisted in:
- first, presenting and explaining the various productivity
decomposition methods used in the literature on individual data
(see slides in Appendix);
- Second, developing the selected decomposition programme on
Stata and explaining its content and the various stages of this
programme to the ITCEQ team, in order that its executives may
use it without depending on the DEFI team.
Key outputs of part two (I.2)
- ITCEQ executives were trained on the decomposition methods
used in the literature.
- In terms of output, ITCEQ has a productivity decomposition
programme under Stata.
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2. Analysis of Outputs
In this first section, a descriptive analysis is conducted on thedatabase of Tunisian businesses from the sample of surveys over
a period ranging from 1997 to 2007. In the next section, the
outcomes from the productivity decomposition are analysed.
2.1 Descriptive Analysis of Tunisia’s IndustrialBusiness Database
All data in the database are derived from annual surveys conducted
by the National Institute of Statistics of Tunisia and made available
to ITCEQ. The database covers sectors of the Tunisian industry from
1997 to 2007. It contains information on production, intermediate
consumption, permanent employment, seasonal employment,
industry sector, the region and capital structure. The transition to
constant prices was carried out using the price indices for production,
value added and 5-digit price indices for intermediate consumption
provided by INS. The business performance indicator used is labour
productivity, obtained from each company, via the ratio of value
added at constant prices over the entire workforce, which comprises
both the permanent workforce and seasonal jobs.
By retaining only the industrial sector, the "raw" initial database has
16 442 remarks, representing 4,464 businesses. Once cleaned
(detailed cleaning procedure in Box 1), the unbalanced panel
database includes 15 202 remarks and 4206 businesses. Table 1
gives the number of businesses per year. It is record low in 2007,
with 1,180 businesses and record high in 2000, with 1,613
businesses.
Table 1: Number of Businesses per Year
Years Number of Businesses
1997 1380
1998 1471
1999 1385
2000 1613
2001 1586
2002 1333
2003 1253
2004 1247
2005 1318
2006 1436
2007 1180
Number of Remarks 15 202
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Table 2 shows the number of businesses by number of years of
presence in the database. Note that this number of years of presence
may not be consecutive. It is found that only 89 firms are present
for all the years, i.e. 11 years running. In addition, a very large number
of enterprises (1,469 i.e. about 35% of businesses) appear only for
one year.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 2: Number of Businesses According to the Number of Years of Presence in the Database
Number of years of presence in the database Number of Businesses In percentage
1 1469 35%
2 561 13%
3 469 11%
4 327 8%
5 322 8%
6 318 8%
7 205 5%
8 178 4%
9 140 3%
10 128 3%
11 89 2%
Total 4206 100%
Table 3: Number of Businesses by Sector
Sector Number of Businesses In percentage
1 Agri-food and Tobacco 561 13%
2 Textile 262 6%
3 Apparel 1236 29%
4 Footwear and Leather 250 6%
5 Timber, Paper and Publishing 283 7%
6 Chemicals and Pharmaceuticals 179 4%
7 Rubber and Plastics 159 4%
8 Non-metal Materials 314 7%
9 Metal Materials 320 8%
10 Equipment, Machines and Electrical Appliances 329 8%
11 Automotive Industry and other Transportation Equipment 102 2%
12 Furniture 211 5%
Table 3 below shows the breakdown of the sample firms by sector.
Most prominently represented are Apparel (29%) and Agri-food (13%)
On their own, they account for 42% of businesses in the sample.
However, the Automotive sector accounts for only 2% of the number
of firms, followed by the Chemicals & Pharmaceuticals, Rubber &
Plastics sectors (4% each).
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The breakdown of 4,206 businesses by size was conducted based
on the criterion of average total employment of each business by
using the quantiles method. The resultant breakdown classifies
companies with a total number of employees not exceeding 23
under the "small" group. In other words, the first third of the sample
firms have, on average, a number of employees not exceeding 23.
In the "average" group (which corresponds to the second third of
businesses), businesses have a number of employees strictly greater
than 23 and not exceeding 77. "Large" group (the last third of sample)
firms have more than 77 employees.
Table 4: Number of Businesses by Size According to the Number of Years of Presence in the Database
Number of years ofpresence in the database
Number Percentage
Total Small Medium Large Small Medium Large
1 1469 732 455 282 50% 31% 19%
2 561 195 205 161 35% 37% 29%
3 469 144 172 153 31% 37% 33%
4 327 84 104 139 26% 32% 43%
5 322 114 106 102 35% 33% 32%
6 318 68 109 141 21% 34% 44%
7 205 27 78 100 13% 38% 49%
8 178 17 67 94 10% 38% 53%
9 140 10 46 84 7% 33% 60%
10 128 3 24 101 2% 19% 79%
11 89 1 15 73 1% 17% 82%
Table 4 shows the breakdown of businesses by size and by the number
of years of presence in the database. The first row of the table shows,
for instance, that among the 1,469 firms present in a single year, half
of them (i.e. 732) fall under the "small" category, about a third (or 455)
belong to the "average" category and 19% (i.e. 282 companies) are
considered "large". Therefore, arrival and disappearance from the
sample (which, it should be recalled, are not necessarily new businesses
or cessation of activities) concern more of small firms. The distribution
by size of companies present for five years generally corresponds to
breakdown by quantile of 4206 businesses in the sample.
Approximately 80% of companies in the database for 11 or 10 years
fall under the "large" business category. On average, companies with
over 77 employees are present in the sample during a number of years
higher than the "average" and especially "small" categories.
Box 1. Cleaning Procedure
The procedure developed was largely inspired by Hall and Mairesse (1995).This eliminates firms that have never filled their VA or employment. In addition, variables with zero, unfilled or negative observations were removed, as well as those with annual growth ratesratios, VA/Total Employment, Intermediate consumption/Total Employment, Income/Total employment or Capital/Total employmentratios greater than 500 % or less than -500%.
155
Table 5 dwells on the breakdown by size of businesses in the
database within the various sectors. For example, the second part
of the table shows that the breakdown in sector 10 (Electrical
Machinery) is closest to the distribution of firms across the database.
30% of companies are indeed small-sized, 36% are medium-sized
and 35% are large. However, the figures in bold or underscored in
gray highlight where the percentages substantially differ from those
that correspond to all the sectors. The highest fall in bold and the
lowest percentages are highlighted in gray. It is found that companies
in the "small" category are relatively more present in the timber, paper
& publishing sector (58%), agri-food (57%), furniture manufacturing
(51%) and metal materials (45%) sectors. However, they are less
present in two sectors: apparel (10%) and footwear and leather
(23%). It is in this leather and footwear sector alone that "medium-
sized" companies are relatively the most active, with a 40% share.
Furthermore, it is only in one sector (food and agricultural) that these
"medium-sized" businesses are relatively less prevalent (21%). Lastly,
companies considered "large" are more strongly represented in
apparel (57%), but relatively less present in timber, paper & publishing
(13%), metal materials (17%) food and agriculture (22%).
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 5: Breakdown of Businesses by Sector and by Size
SectorsNumber Percentage
Total Small Medium Large Small Medium Large
1. Agri-food and Tobacco 561 317 119 125 57% 21% 22%
2. Textile 262 96 103 63 37% 39% 24%
3. Apparel 1236 124 406 706 10% 33% 57%
4. Footwear and Leather 250 57 101 92 23% 40% 37%
5. Timber, Paper & Publishing 283 163 82 38 58% 29% 13%
6. Chemicals and Pharmaceuticals 179 68 62 49 38% 35% 27%
7. Rubber and Plastics 159 61 62 36 38% 39% 23%
8. Non-metal Materials 314 124 109 81 39% 35% 26%
9. Metal Materials 320 145 121 54 45% 38% 17%
10. Electrical Machinery 329 98 117 114 30% 36% 35%
11. Automotive Industry 102 35 28 39 34% 27% 38%
12. Furniture 211 107 71 33 51% 34% 16%
Given that, as already highlighted, "large" businesses stay much longer
in the database than the "medium" and especially "small" categories,
the distribution of businesses by year and by size described in Table 6
shows first the prevalence of large enterprises in the total number of
observations. Indeed, they account for 46% of 15,202 observations in
the entire sample (6,996 observations concerning the category of "large"
businesses), the medium category accounts for 32% (4,882 observations),
while "small" firms make up only 22% of total observations (i.e., 3,324
observations). It is observed that in 2002, 2004 and 2005, "small" firms
are relatively poorly represented (with shares of 16%, 14% and 15%
respectively) mainly to the advantage of "big" companies, especially in
2004 and 2005, given that this category of "large" firms account for
56% and 55% of annual observations for both years, respectively.
Table 7 below shows the breakdown of firms by capital structure
and by size. Among the 4,206 businesses in the sample, 126 (3%)
have part of their capital held by the State and 1,243 (30%) have
part of their capital held by foreign investors. The firms concerned
fall mainly under the "large" category (58% for capital held by the
State and 65% for capital held by a foreign entity).
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Table 8 shows the number of businesses by major region. It is
found that the vast majority of businesses in the sample are located
in the district of Tunis, the North East and Central East. Only
6% of the 4,206 firms are located in the North West, 3% are
located in the South (East and West) and 2% of the sample in the
Centre West.
Table 9 presents the averages and standard deviations of value
added, intermediate consumption, production, number of permanent
employees, total number of employees, capital stock, investment
and labour productivity, both for all businesses in the sample and
by breaking them down by size. The case of Tunisian businesses
confirms what is usually found in the literature, namely that productivity
increases with company size. Indeed, "large" companies have a
higher unweighted average labour productivity (8.78) compared
to "medium" firms (8.71) and "small firms" (8.48).
The value added, intermediate consumption, production and capital
stock of "medium” businesses are 4 times higher than those of
“small” businesses. Instead, they invest 5 times more and employ
only 3.5 times more than "small" firms. The "large" companies have
value added 24 times higher than smaller ones. They invest 28 times
Table 6: Number of Businesses by Year and by Size
Number of years ofpresence in the database
Number Percentage
Total Small Medium Large Small Medium Large
1997 1380 386 457 537 28% 33% 39%
1998 1471 417 478 576 28% 32% 39%
1999 1385 348 467 570 25% 34% 41%
2000 1613 368 586 659 23% 36% 41%
2001 1586 323 568 695 20% 36% 44%
2002 1333 219 449 665 16% 34% 50%
2003 1253 251 361 641 20% 29% 51%
2004 1247 174 380 693 14% 30% 56%
2005 1318 204 387 727 15% 29% 55%
2006 1436 336 417 683 23% 29% 48%
2007 1180 298 332 550 25% 28% 47%
Total (number ofobservations)
15202 3324 4882 6996
Total (in % of No. of obs.)
100% 22% 32% 46%
Table 7: Number of Businesses by Capital Structure and by Size
Corporate capitalstructure
Number Percentage by business type
Total Small Medium Large Small Medium Large
Businesses thathave at least part oftheir capital held bythe State
126(i.e. 3% of 4206 businesses)
24 29 73 19% 23% 58%
investors (businesses) 107 334 802 9% 27% 65%
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more, and hold capital stock 31 times higher, and their total
employment is 17 times higher, than the category of "small" firms.
Consequently, they are characterized by higher capital intensity
(almost 2 times higher than small, and a little over 1.5 times higher
than medium, businesses).This finding may suggest that by using
total factor productivity (TFP) in lieu of labour productivity, the
category of "large" companies may not have the highest average
level of efficiency.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 8: Number of Businesses by Major Region
Regions Number of Businesses In percentage
1 District of Tunis and North East 1829 45%
2 North West 246 6%
3 Centre East 1731 43%
4 Centre West 95 2%
5 South East and West 122 3%
6 Total 4023* 100%
* 183 businesses did not provide information on their location. Hence, the figures available fall short of the total number of businesses in the database, which stands at 4206.
Table 9: Key Statistics for Businesses in the Entire Sample and by Size
By Size Variables Mean Standard Deviation
Small
Value added (constant price) 101 583 303 478
Intermediate consumption (constant price) 329 622 1 438 669
Production (constant price) 428 824 1 681 111
Number of permanent employees 13 6
Total number of employees (permanent and seasonal) 13 6
Capital Stock (constant price) 165 439 282 812
Investment (constant price) 23 277 72 482
Labour Productivity * 8,48 0,90
Medium
Value added (constant price) 427 958 880 480Intermediate consumption (constant price) 1 246 976 2 953 823Production (constant price) 1 670 705 3 670 848Number of permanent employees 43 20Total number of employees (permanent and seasonal) 47 20Capital Stock (constant price) 662 209 1 067 453Investment (constant price) 116 032 328 370Labour Productivity * 8,71 0,90
Large
Value added (constant price) 2 496 077 8 067 454Intermediate consumption (constant price) 6 327 027 22 900 000Production (constant price) 8 807 453 30 100 000Number of permanent employees 205 261Total number of employees (permanent and seasonal) 232 334Capital Stock (constant price) 5 129 195 22 700 000Investment (constant price) 659 287 2 149 993Labour Productivity * 8,78 0,88
EntireSample
Value added (constant price) 1 308 348 5 606 703Intermediate consumption (constant price) 3 384 245 15 900 000Production (constant price) 4 683 511 20 900 000Number of permanent employees 111 198Total number of employees (permanent and seasonal) 125 248Capital Stock (constant price) 2 609 306 15 600 000Investment (constant price) 345 758 1 499 262Labour Productivity * 8,69 0,90
* This is the unweighted average, on all 11 years, expressed in log.
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Table 10 shows unweighted average productivity by sector over the
11 years covered in the sample. Throughout the entire period under
consideration, 9 sectors have an average productivity above that of
all businesses. The most productive among these sectors are
Chemicals and Pharmaceuticals (with an unweighted average of
9.49), followed by Electrical Machinery (9.11) and Rubber and Plastics
(9.06). Only 3 sectors have an average productivity below the
productivity of all businesses in the sample. These are Apparel (with
an average productivity of 8.25), Footwear and Leather (8.45), and
Furniture (8.60).
Table 10: Unweighted Average of Labour Productivity by Sector
Sector Unweighted Average of Labour Productivity
1 Agri-food and Tobacco 8.88
2 Textile 8.72
3 Apparel 8.25
4 Footwear and Leather 8.45
5 Timber, Paper & Publishing 8.89
6 Chemicals and Pharmaceuticals 9.49*
7 Rubber and Plastics 9.06
8 Non-metal Materials 8.94
9 Metal Materials 8.77
10 Electrical Machinery, Machines and Appliances 9.11
11 Automotive Industry and other Transportation Equipment 8.85
12 Furniture 8.60*
Table 11: Average Labour Productivity by Capital Structure
Corporate capital structure Unweighted Average Labour Productivity
Businesses that have at least part of their capital held by the State 9.22
Businesses that have at least part of their capital held by foreign private investors 8.71
Table 11 shows unweighted average productivity by corporate
capital structure. It is found that businesses whose capital is held
in whole or in part by the State or foreign investors have, throughout
the period, an average productivity higher than all businesses.
However, no causal link may be inferred, given especially that, as
shown above, these firms fall mainly under the "large" category of
businesses. It is therefore not surprising to observe a higher average
productivity for both categories of businesses.
Hereafter is the descriptive analysis of the labour productivity trend.
Table 12 provides the weighted average productivity per year
(expressed in log), which is also shown graphically (Graph 1).
During these 11 years, the labour productivity of Tunisian
businesses in our sample rose sharply. Labour productivity
(weighted average) increased from 9.42 in 1997 to 9.67 in 2006
(which is a 25% increase) and 9.91 in 2007 (i.e. 49% increase, still
with respect to 1997). With respect to annual growth rates,
productivity declined only between 2002 and 2003 (5%), between
2003 and 2004 (1%) and between 2004 and 2005 (1%). The strong
productivity growth registered between 2006 and 2007 (+24%) is
quite surprising and should be considered with caution. Indeed,
159
the year 2007 is characterized by a significant turnover of
businesses in the sample. As shown in Table 13, 30% of firms in
2007 were never previously present in the database. It seems that
these arrivals and disappearances of businesses have greatly
contributed to such increase in productivity between 2006 and
2007. Although INS uses a number of procedures to ensure the
representativeness of the samples surveyed, caution must be
exercised in interpreting results when working on databases which
are not from censuses. Furthermore, to avoid distorting the
interpretations, some graphs will be presented: (i) covering the
entire period (i.e. from 1997 to 2007) and (ii) leaving out the last
year (i.e. from 1997 to 2006).
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 12: Labour Productivity Trend for all Businesses in the Sample
YearsWeighted average productivity (in log)
Annual growth rate of weighted averageproductivity
Productivity growth rate with respectto 97
1997 9.42
1998 9.45 3% 3%
1999 9.49 4% 7%
2000 9.58 9% 16%
2001 9.61 3% 19%
2002 9.66 5% 24%
2003 9.61 -5% 19%
2004 9.60 -1% 18%
2005 9.59 -1% 17%
2006 9.67 8% 25%
2007 9.91 24% 49%
Graph 1: Weighted Average of Labour Productivity Trend between 1997 and 2007 (in log)
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Table 13: Number of Years of Presence of Businesses in the Database by Year
No. Of years of presence
1997 1998 1999 2000 2001 2002 2003 2004 2005 2006 2007Distribution in 2007
1 131 111 46 74 47 93 127 96 156 235 253 30%
2 83 116 52 113 121 95 90 94 95 166 97 8%
3 134 129 131 140 130 95 84 126 164 159 115 10%
4 122 133 151 172 125 91 93 113 114 113 81 7%
5 183 195 210 226 231 103 107 97 95 99 64 5%
6 185 194 195 231 251 211 139 136 130 143 93 8%
7 115 132 135 157 176 159 144 116 114 115 72 6%
8 107 129 131 162 168 153 137 138 116 109 74 6%
9 115 121 118 131 128 123 122 121 120 87 74 6%
10 116 122 127 118 120 121 121 121 125 121 68 6%
11 89 89 89 89 89 89 89 89 89 89 89 8%
Total 1380 1471 1385 1613 1586 1333 1253 1247 1318 1436 1180 100%
Graphs 2 show the weighted average labour productivity by sector,
first between 1997 and 2007, and then between 1997 and 2006. If
2007 is disregarded, it will be discovered that labour productivity
fell in five sectors: textiles (sector 2), apparel (sector 3), chemicals
and pharmaceuticals (sector 6), rubber and plastics (sector 7) and
automotive (sector 11). For the first 3 sectors (textiles (2) , apparel
(3) and chemicals and pharmaceuticals (6), the strong productivity
growth registered between 2006 and 2007 helps to avoid the
foregoing cuts and to end up in 2007 with productivity levels higher
than in the beginning of the period (i.e. 1997). In Sector 7 (rubber
and plastics), labour productivity also increased sharply between
2006 and 2007, but not enough to exceed the productivity level of
1997. In addition, a glance at the graphs over the period 1997-2007
reveals that only one sector, the automotive sector (sector 11),
experienced a significant drop in its labour productivity. In contrast,
Labour productivity increased in seven sectors: agri-food (sector
1), leather and footwear (sector 4), timber, paper and publishing
(sector 5), non-metal materials (sector 8), metal materials
(sector 9), electrical machinery (sector 10) and furniture (sector 12).
Among these sectors, labour productivity growth is particularly
marked in the food and agriculture sector (1), timber, paper and
publishing (5), non-metal materials (8), metal materials (9) and
electrical machinery (10).
Graphs 3 show the labour productivity trend by size, first between
1997 and 2007 and then between 1997 and 2006. What has been
described, in the graphs, as "product-small", "product-medium" and
"product-large" corresponds to the weighted average labour
productivity, respectively, of "small", "medium" and "large" firms in
the sample. Although, with respect to unweighted average for the
whole period, Table 9 reveals that the labour productivity of "large"
companies exceeded that of "medium" ones, it is found that the
weighted average productivity of these "medium " businesses (red
solid line) grew faster than that of "large" firms (wide dotted, green).
The labour productivity of "medium" enterprises stood at 9.36 in
1997 and increased to 9.91 in 2006 and to 9.51 in 2007. For the
category of "large" companies, the weighted average of labour
productivity stood at 9.42 in 1997. It increased to 9.65 in 2006 and
to 9.91 in 2007. The labour productivity of "medium" firms exceeded
that of "large" firms from 2001 until 2006. In 2007, the productivity
of "large" businesses once more exceeded that of "medium" firms.
The irregular growth of average productivity of "small" businesses
161
(small blue dots) is due most likely to the substantial arrivals and
disappearances from the sample, predominantly by this category
of companies. Moreover, the strong productivity growth between
2006 and 2007 was recorded mainly by "small" firms and, to a lesser
extent, by "large" firms.
Graphs 4 shows the labour productivity trend by corporate capital
structure between 1997 and 2007 and depicts, in solid line, the
category of businesses whose capital is wholly held by the State,
and in dotted line, the category of firms with at least part of their
capital held by foreign investors. It is clear that the productivity
of domestic firms rose more sharply than that of companies
with foreign capital. In 1997, the productivity of domestic
businesses stood at 9.32. It increased to 9.72 in 2006 and to
almost 10 in 2007. For companies with foreign capital, it increased
from 9.58 in 1997 to 9.68 in 2006 and 9.82 in 2007. Between
1997 and 2003, the productivity of companies having foreign
capital is higher than that of domestic firms. Starting 2003, the
reverse is true: labour productivity of domestic firms becomes
higher than that of firms with foreign capital. This mind-boggling
outcome is interesting, and requires a more detailed specific
analysis. Indeed, it is generally expected that businesses owned
in part by foreign investors will experience more substantial
productivity growth.
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Graphs 2: Trend in Weighted Average of Labour Productivity between 1997 and 2007 (in log)Between 1997 and 2006 (in log)
Entre 1997 et 2006 (en log)
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Graphs 3: Trend in Weighted Average of Labour Productivity by Sizebetween 1997 and 2007 (in log)
Entre 1997 - 2006 (en log)
Graph 4: Trend in Weighted Average of Labour Productivity by Corporate Capital Structure (in log)
164
2.2 Productivity Decomposition Analysis
The purpose of this section is to identify the source of changes
in productivity. The idea here is, specifically, to know whether
productivity growth arises from increased productivity within
businesses of the sample or ensues from reallocation.
Labour productivity growth in businesses may be related
to either:
- unanticipated cyclical changes in demand by businesses, which
generally account for frequent "unintentional" slumps in labour
productivity;
- labour market rigidities that can slow down the adaptation of
the number of employees (upward or downward) to changes in
production; or
- a set of firm-specific decisions that can lead to improved
productivity. These include, for example, improving the standard
of employee training, investing in the procurement of more efficient
machines, use of better quality inputs, corporate reorganization,
redundancy-related decisions, etc.
The phenomena of reallocation may ensue from inter-sector
changes (some sectors develop while others stagnate or decline),
or intra-sector changes, i.e. market share variations as well corporate
entries and exits occur within each sector. For a long while, because
only sector data (from either domestic or international sources
provided by UNIDO) were available, the reallocation analysis focused
on inter-sector changes, given that the homogeneous firm
assumption posited by both traditional international trade theories
and the New Trade theory (Krugman, 1979, Helpman and Krugman,
1987) does not help to explain, theoretically, the possibility of intra-
industry reallocation. The recent development of the "New New
Trade" theory, initiated in particular by Melitz (2003), and characterized
by consideration of the heterogeneity of businesses within sectors,
justified theoretically, that the analysis should focus on changes
within firms. Access to the individual databases of companies helped
to develop empirical analyses in furtherance of these theoretical
advances.
Hence, the main lessons learned from recent theoretical and empirical
developments in the literature are only within the same industry.
There are companies that can be very outstanding, owing to their
size, degree of integration into the international economy, level of
productivity, etc. and that, in this context, any change (trade reform,
business environment, change in international demand, increased
competition, etc..), will impact differentially on these businesses and
necessarily engender reallocations within sectors. The predominant
concept from the literature is that these intra-industry reallocations
would be of much greater magnitude than those occurring between
sectors. In this theoretical framework, Melitz (2003, cited above) has
shown, for instance, that opening up to international trade leads to
increased market shares for businesses that were initially the most
productive to the detriment of the less productive ones, which
disappear or see their market share shrink. For these authors of
"New New Trade", changes in the aggregate productivity of an
economy are due mainly to the reallocation of such phenomena
within industries, especially when it comes to savings open to
international trade.
Upon its accession to the WTO in March 1995 and the entry into
force of a number of trade agreements, both within the multilateral
framework (GAFTA, which took effect in January 1998, the Agadir
Process, the AMU) and on a bilateral basis (the Euro-Mediterranean
Association Agreement, implemented starting January 1996, the
series of agreements with Egypt, Morocco and Jordan, all three
implemented in 1999), Tunisia undertook to eliminate these customs
duties. Between 1995 and 2004, the simple average of tariffs fell by
22%. Consequently, one can therefore wonder, as recent theoretical
developments would suggest, whether this openness to international
trade has resulted in the huge, concomitant productivity gains from
the phenomenon of reallocation.
2.2.1. Principle of Decomposition Methods
In the literature, the three main methods used are those of Foster,
Haltiwanger Krizan (FHK, 1998 and 2001), Griliches and Regev (GR,
1995) and, more recently, Pavcnik (2002). Although the FHK method
is the most comprehensive, it requires, as does also the GR method,
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T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
knowledge of the arrival and disappearance of businesses. Given
that data on Tunisian firms do not allow for the identification of "real"
arrivals and disappearances , the only method applicable in this case
is Pavcnik's.
This method consists in decomposing aggregate productivity in the
following manner:
(1)
with , the weighted average of productivity (expressed in log) in
year t,
(2)
, unweighted average of productivity in year t, , market share
of business i in sample, , average market share of businesses in
the sample and , productivity of business i, expressed in log.
The employment or production criterion may be used in obtaining
the market share. In this research work, production26 was chosen.
This decomposition may be carried out either through labour
productivity or through total factor productivity. In this case, only
labour productivity was used.
This decomposition shows that the weighted average productivity
can be decomposed into two terms:
- The first term (i.e.) ) is the unweighted average of productivity
of all firms in the sample. This first term is what is known in the
literature as a "within" effect. It measures the contribution of
business productivity growth.
- The second term (i.e. ) which is called
the covariance term, takes into account the difference in the
company’s market share relative to the average share of firms
in the sample and the productivity gap of the firm with respect
to the unweighted average productivity of the sample. Hence,
the latter term determines the contribution to the productivity
growth of the sample ensuing from the reallocation of market
shares among firms of different productivity levels. The
contribution of this reallocation effect is particularly crucial, given
that companies with relatively high (/ low) productivity, i.e. above
(/ below) the unweighted average of the sample, have market
shares relatively bigger (/ smaller) than (i.e. above (/ below) the
average market share of firms in the sample).
If the first term is positive, it means that, on average, companies
have increased their productivity. If the second term is positive, it
indicates that a higher proportion of goods is produced by more
efficient firms. Although the corporate data used in this study are
from a sample, one might expect, according to the predictions of
theoretical literature, that against the backdrop of liberalization, the
second term is positive and it increases over time, over the period
considered.
2.2.2. Outputs
This decomposition method was applied (i) across the entire
sample, (ii) by sector, (iii) by size and (iv) by corporate capital
structure. In all cases, the results are shown in terms of change
from the start year, i.e. 1997. In the 4 tables below, the second
column indicates changes in aggregate productivity with respect
to 1997. The following 2 columns correspond to variations of the
first and second term in the decomposition. As required by the
decomposition equation, the sum, online, of columns (3) and (4)
corresponds to column (2).
26 By applying this method on data from the UK, Disney et al. (2003) shows that the use of production, alternately with employment, only changes the results very marginally.
166
Table 14 shows the outcome of the entire sample. Column (2),
which indicates changes in aggregate labour productivity for all
businesses, is the last column of Table 12 already presented above.
It is found that much of the productivity growth is derived from
the reallocation effect. In 2006, the 25% aggregate labour
productivity growth rate were due to the 8% from productivity
growth within businesses, and 17% from the reallocation of
resources from less efficient to the most efficient firms. In other
words, 67% of the variation in aggregate productivity over 10 years
(97-2006) is due to the increase in the covariance term. In 2007,
the same share stood at 72%. Although this covariance term did
not increase regularly throughout the period, it is always positive
(except only for the first two years), which shows that reallocation
plays in the right direction, i.e. the most productive firms are
developing and/or the least productive ones have decreasing
market shares.
T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 14: Decomposition of Aggregate Productivity Growth for the Entire Sample
Years Aggregate productivity growthVariation in unweighted Productivity (First term)
Variation inCovariance(Second term)
1997 0.000 0.000 0.000
1998 0.023 0.055 -0.031
1999 0.071 0.072 -0.001
2000 0.153 -0.038 0.191
2001 0.183 0.043 0.140
2002 0.235 0.124 0.112
2003 0.183 0.126 0.057
2004 0.172 0.109 0.062
2005 0.164 0.079 0.085
2006 0.249 0.081 0.168
2007 0.486 0.138 0.348
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T U N I S I A N I N S T I T U T E O F C O M P E T I T I V E N E S S A N D Q U A N T I T A T I V E S T U D I E S
Table 15: Decomposition of Aggregate Productivity Growth by Sector
Sectors Years Agr.Pdt Unwghtd.Pdt
Cov. Sectors Years Agr.Pdt Unwghtd.Pdt
Cov.
1 1997 0.000 0.000 0.000 7 1997 0.000 0.000 0.000
Agri-food &Tobacco
1998 0.043 0.063 -0.020
Rubber andPlastics
1998 0.155 0.197 -0.043
1999 0.044 0.007 0.037 1999 0.226 0.183 -0.032
2000 0.100 0.036 0.063 2000 0.226 0.134 0.092
2001 0.224 0.147 0.077 2001 0.127 -0.017 0.144
2002 0.366 0.318 0.048 2002 0.300 0.419 -0.119
2003 0.456 0.306 0.150 2003 -0.186 0.180 -0.366
2004 0.387 0.396 -0.010 2004 -0.118 0.149 -0.267
2005 0.261 0.219 0.041 2005 -0.311 0.014 -0.326
2006 0.304 0.077 0.227 2006 -0.301 0.076 -0.376
2007 0.303 0.066 0.237 2007 -0.120 0.120 -0.240
2 1997 0.000 0.000 0.000 8 1997 0.000 0.000 0.000
Textile
1998 -0.172 -0.094 -0.078
Non-metalMaterials
1998 0.037 0.151 -0.114
1999 -0.150 0.033 -0.183 1999 -0.085 0.089 -0.175
2000 0.172 0.101 0.072 2000 0.254 0.130 0.125
2001 0.266 0.187 0.080 2001 0.397 0.354 0.043
2002 0.281 0.424 -0.143 2002 0.552 0.400 0.152
2003 0.168 0.277 -0.109 2003 0.527 0.556 -0.029
2004 0.099 0.275 -0.176 2004 0.509 0.653 -0.144
2005 -0.008 0.205 -0.213 2005 0.407 0.562 -0.155
2006 -0.116 0.100 -0.216 2006 0.565 0.585 -0.019
2007 0.164 0.100 0.044 2007 0.700 0.608 0.092
3 1997 0.000 0.000 0.000 9 1997 0.000 0.000 0.000
Agri-food &Tobacco
1998 0.052 0.091 -0.039
MetalMaterials
1998 0.068 -0.053 0.121
1999 0.240 0.093 0.146 1999 0.281 0.057 0.224
2000 0.244 -0.077 0.321 2000 0.236 -0.124 0.360
2001 0.294 0.056 0.237 2001 0.220 -0.215 0.435
2002 0.251 0.100 0.150 2002 -0.028 -0.164 0.136
2003 -0.061 0.111 -0.172 2003 0.067 -0.168 0.235
2004 -0.159 0.022 -0.181 2004 0.198 -0.055 0.253
2005 -0.247 -0.033 -0.213 2005 0.527 -0.166 0.693
2006 -0.076 -0.004 -0.072 2006 0.742 -0.311 1.052
2007 0.654 -0.006 0.661 2007 1.236 -0.257 1.493
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4 1997 0.000 0.000 0.000 10 1997 0.000 0.000 0.000
Footwear andLeather
1998 0.220 0.034 0.186
ElectricalMachineryand appliances
1998 -0.094 0.016 -0.110
1999 0.250 0.101 0.148 1999 0.117 0.156 -0.039
2000 0.211 0.006 0.206 2000 0.269 0.165 0.104
2001 0.209 0.028 0.180 2001 0.267 0.232 0.035
2002 0.023 -0.120 0.144 2002 0.287 0.249 0.038
2003 0.379 0.036 0.343 2003 0.163 0.374 -0.211
2004 0.226 0.016 0.210 2004 0.345 0.359 -0.015
2005 0.071 -0.027 0.098 2005 0.356 0.425 -0.069
2006 0.302 0.004 0.298 2006 0.469 0.364 0.105
2007 0.333 0.157 0.176 2007 0.504 0.636 -0.132
5 1997 0.000 0.000 0.000 11 1997 0.000 0.000 0.000
Timber, Paper& Publishing
1998 0.031 0.042 -0.012
Automotive Industryand otherTransportationEquipment
1998 -0.131 -0.060 -0.071
1999 0.081 0.057 0.024 1999 -0.370 -0.091 -0.279
2000 -0.014 0.012 -0.026 2000 -0.082 0.028 -0.110
2001 0.012 0.156 -0.143 2001 -0.090 0.048 -0.138
2002 0.045 0.113 -0.068 2002 -0.216 0.074 -0.290
2003 0.177 0.086 0.091 2003 -0.297 -0.300 0.003
2004 0.164 0.172 -0.008 2004 -0.289 0.087 -0.376
2005 0.278 0.102 0.176 2005 -0.332 0.041 -0.372
2006 0.209 0.148 0.062 2006 -0.454 -0.233 -0.221
2007 0.398 0.251 0.147 2007 -0.190 -0.069 -0.121
6 1997 0.000 0.000 0.000 12 1997 0.000 0.000 0.000
Chemicalsand Pharma-ceuticals
1998 -0.051 -0.079 0.028
Furniture
1998 0.064 0.135 -0.071
1999 -0.020 -0.019 -0.001 1999 0.069 0.108 -0.040
2000 -0.326 0.100 -0.426 2000 0.230 0.118 0.112
2001 -0.005 0.237 -0.241 2001 0.273 0.194 0.079
2002 -0.382 0.264 -0.645 2002 0.322 0.348 -0.027
2003 -0.847 0.271 -1.118 2003 0.008 0.018 -0.010
2004 -0.094 0.414 -0.509 2004 -0.007 0.064 -0.071
2005 -0.358 0.272 -0.630 2005 0.208 0.263 -0.055
2006 -0.685 0.153 -0.838 2006 0.217 0.335 -0.118
2007 0.173 0.224 -0.051 2007 0.521 0.513 0.007
Table 15 contains the outcomes of labour productivity decomposition
by sector. While it is true that, for the entire sample, reallocation
contributed significantly to aggregate productivity growth, it is worth
underscoring also that such assertion still needs to be verified in
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the sectors. In fact, it is only in 2 industries (footwear and leather
(sector 4) and metal materials (sector 9)), that changes in the
covariance term are always positive throughout the period and
higher than corporate productivity. However, in the following six
sectors: textiles (sector 2), chemicals and pharmaceuticals (sector
6), rubber and plastics (sector7), non-metal materials (sector 8),
electrical machinery (sector 10) and furniture (sector 12), corporate
productivity increased, while the covariance term had a negative
impact on the variation of aggregate productivity. In the timber,
paper and publishing sector (sector 5), the dominant effect is labour
productivity growth within businesses. In the agri-food sector
(sector 1), productivity growth is also due, throughout the period,
to the productivity growth of businesses, except for the last 2 years
(2006 and 2007) during which contributions from the covariance
term were particularly significant. Lastly, in two sectors, the apparel
(sector 3) and automotive (sector 11), these two terms (corporate
productivity and covariance), played a negative role on the change
in aggregate labour productivity.
The outcomes of decomposition by size are presented in Table 16.
The impact of reallocation contributed significantly to the aggregate
labour productivity growth for the "average" and "large" categories
of businesses. With the exception of 1998, the variation of the
covariance term was indeed always positive for these two groups
of firms. For the "small" category, that term varied positively only
for four years (2000, 2001, 2005 and 2007). The strong growth
of the covariance term in 2007 should be considered with caution,
given, as already underscored above, the crucial survey sample
rotation particularly relevant to "small" businesses. These results
also show that "medium"-sized businesses, for the most part,
increased their unweighted labour productivity. It would be
, interesting to understand the factors that prompted them to im-
prove their efficiency and the means by which they achieved it.
Table 17 shows the results of the decomposition of aggregate
labour productivity by corporate capital structure. It is fascinating
to observe that, in the sample, the reallocation effect tended to
contribute to aggregate productivity growth only for businesses
that are entirely domestic. For firms with part of their capital held
by foreign investors, the variation in the covariance term is positive
only for 4 years (2000, 2001, 2002 and 2007).
With regard specifically to entirely domestic businesses, the 40%
increase in aggregate labour productivity in 2006 can be broken
down as follows: 7% accounts for labour productivity growth within
businesses and 33% is derived from the reallocation effect. In 2007,
the 68% increase in aggregate productivity ensued from productivity
growth within businesses (14%) and the reallocation effect (54%).
Table 16: Decomposition of Aggregate Productivity Growth by Size
Size YearsVariation inAggregate Productivity
Variation inUnweighted Productivity (First term)
Variation inCovariance(Second term)
Small
1997 0.000 0.000 0.000
1998 -0.081 0.032 -0.113
1999 -0.679 0.057 -0.735
2000 0.091 -0.013 0.104
2001 0.343 0.065 0.278
2002 -0.615 0.031 -0.646
2003 -0.483 -0.039 -0.444
2004 -0.295 -0.059 -0.236
2005 0.248 0.052 0.196
2006 -0.554 0.018 -0.572
2007 1.581 0.154 1.427
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Size YearsVariation inAggregate Productivity
Variation inUnweighted Productivity (First term)
Variation inCovariance (Second term)
Medium
1997 0.000 0.000 0.000
1998 0.064 0.081 -0.018
1999 0.125 0.077 0.049
2000 0.204 -0.049 0.253
2001 0.218 0.046 0.173
2002 0.377 0.200 0.177
2003 0.410 0.251 0.159
2004 0.378 0.205 0.174
2005 0.278 0.170 0.108
2006 0.560 0.161 0.399
2007 0.147 0.143 0.004
Large
1997 0.000 0.000 0.000
1998 0.022 0.048 -0.026
1999 0.088 0.060 0.028
2000 0.151 -0.063 0.214
2001 0.176 -0.007 0.183
2002 0.232 0.040 0.192
2003 0.171 0.064 0.106
2004 0.157 0.023 0.134
2005 0.152 -0.036 0.188
2006 0.225 0.024 0.201
2007 0.488 0.095 0.393
Table 17: Decomposition of Aggregate Productivity by Corporate Capital Structure
Capital Structure
YearsVariation inAggregate Productivity
Variation inUnweighted Productivity (First term)
Variation inCovariance (Second term)
DomesticFirms
1997 0.000 0.000 0.000
1998 0.095 0.054 0.041
1999 0.102 0.063 0.038
2000 0.150 -0.032 0.183
2001 0.241 0.049 0.192
2002 0.285 0.136 0.150
2003 0.287 0.116 0.171
2004 0.325 0.122 0.203
2005 0.388 0.094 0.294
2006 0.399 0.073 0.326
2007 0.681 0.144 0.537
Firms withforeign capital
1997 0.000 0.000 0.0001998 -0.086 0.055 -0.1411999 0.016 0.096 -0.0802000 0.127 -0.050 0.1772001 0.079 0.031 0.0482002 0.137 0.101 0.0372003 0.024 0.141 -0.1172004 -0.044 0.087 -0.1312005 -0.132 0.053 -0.1862006 0.040 0.095 -0.0552007 0.236 0.126 0.110
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3. Conclusion
In this study, the labour productivity of Tunisia’s industrial sectorcompanies between 1997 and 2007 was analysed using a sample
of individual firms from annual surveys. The key results of this
analysis are as follows:
First, the aggregate labour productivity of Tunisian businesses
rose sharply. It increased by 25% between 1997 and 2006 (and
by 49% between 1997 and 2007, although the past year should
be considered with extreme caution, given that 30% of the sample
was renewed);
Second, at the sector level, aggregate labour productivity
increased in seven industries (agri-food, leather and footwear,
timber, paper and publishing, non-metal materials, metal materials,
electrical machinery and furniture). However, if year 2007 is
disregarded, aggregate productivity fell in five sectors (textiles,
apparel, chemicals and pharmaceuticals, rubber, plastics and
automotive);
Third, while unweighted average productivity throughout the period
is higher for "large" firms than for "average" ones, aggregate
productivity grew faster for "medium"-sized businesses than for
"large" firms. From 2003 to 2006, the aggregate labour productivity
of "average" businesses exceeds that of "large ones;
Fourth, the aggregate labour productivity of domestic firms rose
more sharply than that of companies with at least part of their capital
held by foreign investors; and
Lastly, the decomposition results highlighted the role of resource
reallocation from less efficient to more efficient businesses in
boosting aggregate labour productivity across the entire sample.
The 25% productivity growth rate between 1997 and 2006 is
accounted for by 8% in labour productivity growth within businesses
and 17% from the reallocation effect. This is true especially for
domestic firms and "medium-" and "large-"sized firms. However,
at the sector level, this result is only true for two industries (footwear
and leather, metal materials). Labour productivity growth within
businesses involved a larger number of sectors (food and
agriculture, textiles, timber, paper and publishing, chemicals and
pharmaceuticals, rubber and plastics, non-metal materials, electrical
machinery and furniture).
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